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The Leland–Toft optimal capital structure model under Poisson observations


This paper revisits the optimal capital structure model with endogenous bankruptcy, first studied by Leland (J. Finance 49:1213–1252, 1994) and Leland and Toft (J. Finance 51:987–1019, 1996). Unlike in the standard case where shareholders continuously observe the asset value and bankruptcy is executed instantaneously without delay, the information of the asset value is assumed to be updated periodically at the jump times of an independent Poisson process. Under a spectrally negative Lévy model, we obtain the optimal bankruptcy strategy and the corresponding capital structure. A series of numerical studies provide an analysis of the sensitivity, with respect to the observation frequency, of the optimal strategies, optimal leverage and credit spreads.


The study of capital structures dates back to the seminal work by Modigliani and Miller [45] which shows that in a frictionless economy, the value of a firm is invariant to the choice of capital structures. While the Modigliani–Miller (MM) theory is regarded as an effective starting point for research on capital structures and has provided valuable insights in the field, it is not directly applicable to businesses. In reality, the selection of capital structures is not perfectly random. Instead, it depends significantly on factors such as industry type, country and corporate law. In the field of corporate finance, various approaches have been taken to explain how much debt a firm should issue. A reasonable conclusion can be obtained only after challenging some of the assumptions of the classical MM theory.

The trade-off theory is one well-known approach for the study of capital structures. While various frictions may affect a firm’s decisions, bankruptcy costs and tax benefits are believed to be the most important factors. By issuing debt, bankruptcy costs increase, while at the same time the firm can enjoy tax shields for coupon payments to the bondholders. The trade-off theory states that firms issue the appropriate debt to solve the trade-off between minimising bankruptcy costs and maximising tax benefits. To formulate this optimisation problem, one needs an efficient and realistic way of modelling not only bankruptcy, but also tax benefits, which depend heavily on the dynamics of the firm’s asset value. For more details on the trade-off theory and its review, see e.g. Frank and Goyal [27], Ju et al. [30] and Kraus and Litzenberger [32].

Classically, there are two models of bankruptcy in credit risk: the structural approach and the reduced-form approach (see Bielecki and Rutkowski [12, Sects. 1.4, 3.3, 3.6 and Part III]). The former, first proposed by Black and Cox [14], models the bankruptcy time as the first time the asset value goes below a fixed barrier. The latter models it as the first jump epoch of a doubly stochastic process (known hereafter as a Cox process) where the jump rate is driven by another stochastic process. Both approaches were developed extensively in the 2000s and are now commonly used throughout the asset pricing and credit risk literature. An extension of the structural approach, which we call the excursion (Parisian) approach, models the bankruptcy time as the first instance in which the amount of time the asset value stays continuously below a threshold exceeds a given grace period. Motivated by the Parisian option, this is sometimes called the Parisian ruin (see Chesney et al. [20]). In the corporate finance literature, the approach has been used to model the reorganisation process (Chap. 11), as in Broadie et al. [16] or François and Morellec [26]. Here, reorganisation is undertaken whenever the asset value is below a threshold; although there is a chance of recovering to return above the threshold, if the reorganisation time exceeds the grace period, the firm is liquidated. For more information, see the literature review in Sect. 1.3.

A new model of bankruptcy

This paper considers the scenario where asset value information is updated only at epochs \((T_{n}^{\lambda })_{n \geq 1}\) given by the jump times of a Poisson process \((N^{\lambda }_{t})_{t \geq 0}\) with fixed rate \(\lambda \). Given a bankruptcy barrier \(V_{B}\) chosen by the equity holders, bankruptcy is triggered at the first update time where the asset process \((V_{t})_{t \geq 0}\) is below \(V_{B}\), i.e., at

$$\begin{aligned} \inf \{ T_{i}^{\lambda }: V_{T_{i}^{\lambda }} < V_{B} \}. \end{aligned}$$

This can also be written as the classical bankruptcy time

$$\begin{aligned} \inf \{ t > 0: V^{\lambda }_{t} < V_{B} \} \end{aligned}$$

of the asset value if the latter is only updated at \((T_{n}^{\lambda })_{n \geq 1}\), i.e., for

$$\begin{aligned} V^{\lambda }_{t} := V_{T^{\lambda }_{N^{\lambda }_{t}}}, \qquad t \geq 0. \end{aligned}$$

Here \(T^{\lambda }_{N^{\lambda }_{t}}\) is the most recent update time before \(t\). In Fig. 1, we plot sample paths of \((V_{t})_{t \geq 0}\), \((V_{t}^{\lambda })_{t \geq 0}\), \((T_{n}^{\lambda })_{n \geq 1}\) and the corresponding bankruptcy time.

Fig. 1

Sample paths of the asset value \((V_{t})_{t \geq 0}\) (black lines) and \((V_{t}^{\lambda })_{t \geq 0}\) (horizontal blue lines) along with the Poisson arrival times \((T_{n}^{\lambda })_{n \geq 1}\) (indicated by dotted vertical lines labelled \(T_{i}\) on the \(x\)-axis). The red zone \((0, V_{B})\) is given by the rectangle colored in red. The asset values at bankruptcy and other observation times are indicated by the red circle and blue triangles, respectively. Here, the bankruptcy time corresponds to \(T_{1}^{\lambda }\), but the asset value has crossed \(V_{B}\) before and then recovered back before \(T_{1}^{\lambda }\). Note that \((V_{t}^{\lambda })_{t \geq 0}\) has a positive jump at \(T_{6}^{\lambda }\)

The bankruptcy model (1.1) is closely related to the reduced-form and excursion approaches reviewed above:

1) The bankruptcy time (1.1) is equivalent to the Parisian ruin with the (constant) grace period replaced with an exponential time clock, the first epoch being the time spent continuously below \(V_{B}\) for more than an independent exponential time. For more details, see Appendix A.

2) It is also equivalent to the bankruptcy time in a reduced-form credit risk model where the bankruptcy time is the first jump time of a Cox process with hazard rate given by \(h_{t} := \lambda \mathbf{1}_{\{V_{t} < V_{B} \}}\), \(t \geq 0\). As in Fig. 1, the region \((0, V_{B})\) can be seen as the “red zone”; here, bankruptcy is triggered at rate \(\lambda \), whereas in the “healthy zone” \((V_{B}, \infty )\), this probability is negligible.

There are several motivations for considering the bankruptcy strategy (1.1) for the study of capital structures.

First, in reality, it is not possible to continuously observe the accurate status of a firm and make bankruptcy decisions instantaneously. In addition, unlike in the case of American option pricing for which computer programs can be set up to exercise automatically, in our case, information is acquired by humans. As observed in the literature of rational inattention (Sims [52]), the amount of information a decision maker can capture and handle is limited, and instead they rationally decide to stay with imperfect information. Taking a bankruptcy decision requires complex information, and it is more realistic to assume that the information for the decision makers is updated only at random discrete times. While they are expected to respond promptly, delays are inevitable and possibly have a significant impact on bankruptcy costs.

Second, the majority of the existing literature assumes continuous observation using a continuous asset value process; in this case, the asset value at bankruptcy is in any event precisely \(V_{B}\). Unfortunately, it is unreasonable to assume that one can precisely predict the asset value at bankruptcy, which is in reality random. The randomness can be realised by adding negative jumps to the process. We underline that in our model, this randomness can also be achieved by any choice (continuous or càdlàg) of the underlying process. See Fig. 6 in Sect. 6.

Third, this model generalises the classical model and allows more flexibility by having one more parameter \(\lambda \). The classical structural model (with instantaneous liquidation upon downcrossing the barrier) corresponds to the case \(\lambda = \infty \), and the no-bankruptcy model to the case \(\lambda = 0\). With careful calibration of \(\lambda \), the model can potentially estimate the bankruptcy costs and tax benefits more precisely. Typically, for calibration, credit spread data is used. As shown in the numerical results (see Fig. 8), a variety of term structures can be achieved by choosing the value of \(\lambda \).

Finally, thanks to the equivalence of our bankruptcy time with the classical bankruptcy time (1.2) of the process \((V^{\lambda }_{t})_{t \geq 0}\), this research can be considered a contribution to the classical structural approach. Existing results featuring asset value processes with two-sided jumps are rather limited. However, we provide a new analytically tractable case for \((V^{\lambda }_{t})_{t \geq 0}\), containing two-sided jumps even when \((V_{t})_{t \geq 0}\) does not have positive jumps (see Fig. 1). By appropriately selecting the driving process \((V_{t})_{t \geq 0}\) as well as \(\lambda \), it is possible to construct a wide range of stochastic processes with two-sided jumps.

Contributions of the paper

Our model is built based on the seminal paper by Leland and Toft [39], with a feature of endogenous default. While Leland’s [38] framework is used more frequently and certainly more mathematically tractable, its extension [39] more accurately captures the flow of debt financing by avoiding the use of perpetual bonds assumed in [38].

In addition, while the majority of papers in financial economics assume a geometric Brownian motion for the asset value \((V_{t})_{t \geq 0}\), we follow the works of Hilberink and Rogers [28], Kyprianou and Surya [37] and Surya and Yamazaki [54] and consider an exponential Lévy process with arbitrary negative jumps (i.e., a spectrally negative Lévy process). Although it is more desirable to also allow positive jumps as in Chen and Kou [19], as discussed in [28], negative jumps occur more frequently and effectively model the downward risks. With the spectrally negative assumption, semi-explicit expressions of the equity value as well as the optimal bankruptcy threshold are elicited, without focusing on a particular set of jump measures. Again, see the discussion above on how our model is capable of modelling the two-sided jump case in the classical structural approach, even when a spectrally negative Lévy process is used for \((V_{t})_{t \geq 0}\). For a more general study of financial models using Lévy processes, the reader should refer to Cont and Tankov [21, Chaps. II and III].

To solve our problem, recent developments of the fluctuation theory of Lévy processes are utilised. First, the firm/debt/equity values are expressed in terms of the so-called scale functions, which exist for a general spectrally negative Lévy process. These permit direct computation of the optimal bankruptcy barrier and the corresponding firm/debt/equity values.

With these analytical results, a sequence of numerical experiments can be conducted. Here, to easily comprehend the impacts of the parameters describing the problem, we use a (spectrally negative) hyperexponential jump diffusion (a mixture of Brownian motion and i.i.d. hyperexponentially distributed jumps), for which the scale function can be written as a sum of exponential functions. The equity/debt/firm values can be written explicitly and the optimal bankruptcy barrier can be computed instantaneously by a classical bisection method. The optimal capital structure is obtained by solving the two-stage optimisation problem as proposed in [39]. In addition, with numerical Laplace inversion, we also obtain the term structures of credit spreads and the density/distribution of the bankruptcy time and the corresponding asset value. Because various numerical experiments have already been conducted in other papers, we focus here on analysing the impacts of the frequency of observation \(\lambda \). We verify the convergence to the classical case of [28, 37] and also observe monotonicity, with respect to \(\lambda \), of the bankruptcy barrier, the firm value under the optimal capital structure, the optimal leverage and the credit spread.

Related literature

Before concluding this section, we review several relevant papers motivating our problem.

The most relevant paper, to the best of our knowledge, is François and Morellec [26] in which the authors model the reorganisation process (Chap. 11) using the excursion approach with a deterministic grace period as described above. Broadie et al. [16] consider a similar model with an additional barrier for immediate liquidation upon crossing, whereas Moraux [46] considers a variant of [26] using the occupation time approach, in which distress level accumulates without being reset each time the asset process recovers to a healthy state. These papers are based on Leland [38], with perpetual bonds and asset values driven by geometric Brownian motions for mathematical tractability. However, computation of the solutions is significantly more challenging than the classical structural approach and hence most papers rely on numerical approaches. In the present paper, on the other hand, semi-analytical solutions for a more general asset value process with jumps are obtained as a result of the use of Poisson arrival times for the update times.

This paper is also motivated by Duffie and Lando [22] who model the asymmetry of information between firms and bond investors. The authors assume that bond investors cannot observe the firm’s assets directly and instead receive only periodic and imperfect accounting reports on the firm’s status. Under these assumptions, the authors successfully explain the non-zero credit spread limit.

Regarding the study of Lévy processes observed at Poisson arrival times, there has been substantial progress in the last few years. Recently, Albrecher and Ivanovs [1] investigated close links between Lévy processes observed continuously and periodically. In results similar to those for the classical hitting time at a barrier, they found that the exit identities under periodic observation can be obtained if the Wiener–Hopf factorisation is known. In particular, when focusing on the spectrally one-sided case, these can be written in terms of the scale function. For the results of our paper, we use the joint Laplace transform of the bankruptcy time (1.1) and the asset value at that time, which is obtained in [2, 1]. In addition, we obtain the resolvent measure killed at the first Poisson downward passage time (1.1) for the computation of tax benefits.

Regarding the optimal stopping problems under Poisson observations, perpetual American options have been studied by Dupuis and Wang [23] for the geometric Brownian motion case. This has recently been generalised to the Lévy case by Pérez and Yamazaki [49]. Several key studies have been performed on the application of scale functions in optimal stopping in a continuous observation setting (see e.g. Alili and Kyprianou [3], Avram et al. [7], Long and Zhang [43], Rodosthenous and Zhang [51] and Surya [53, Chap. 6]). The periodic observation model is more frequently used in the insurance community, in particular in the optimal dividend problem (see Avanzi et al. [5, 6] and Noba et al. [47]).

To the best of our knowledge, this is the first attempt to introduce Poisson observations in the problem of capital structures. We believe the techniques used in this paper can be used similarly in related problems described above when a Poisson observation scheme is introduced.

Organisation of the paper

The organisation of this paper is as follows. In Sect. 2, we present formally the main problem that we work on in this article. In Sect. 3, we compute the equity value using the scale function, and in Sect. 4, we identify the optimal barrier. Section 5 considers the two-stage problem to obtain the optimal capital structure. Section 6 deals with numerical examples confirming the theoretical results. Section 7 concludes the paper. Long proofs are deferred to Appendices B and C.

Problem formulation

Let \((\Omega , \mathcal{F}, \mathbb{P})\) be a complete probability space hosting a Lévy process \(X=(X_{t})_{t\ge 0}\). The value of the firm’s asset is assumed to evolve according to an exponential Lévy process given, for the initial value \(V > 0\), by

$$ V_{t} := V e^{X_{t}},\qquad t\geq 0. $$

Let \(r > 0\) be the positive risk-free interest rate and \(0 \leq \delta < r\) the total dividend rate to the firm’s investors. We assume that the process \((e^{-(r-\delta ) t} V_{t})_{t \geq 0}\) is a ℙ-martingale.

The firm is partly financed by debt with a constant debt profile: it issues, for some given constants \(p, m > 0\), new debt at a constant rate \(p\) with maturity profile \(\varphi (s) := m e^{-ms}\). In other words, the face value of the debt issued in the small time interval \((t, t+\mathrm{d}t)\) that matures in the small time interval \((t+s, t+s+\mathrm{d}s)\) is approximately given by \(p \varphi (s) \mathrm{d}t \mathrm{d}s\). Assuming an infinite past, the face value of debt held at time 0 that matures in \((s, s+ \mathrm{d}s)\) becomes

$$\begin{aligned} \bigg( \int _{-\infty }^{0} p \varphi (s-u) \mathrm{d}u \bigg) \mathrm{d}s = p e^{-m s} {\mathrm{d}}s, \end{aligned}$$

and the face value of all debt is a constant value, given by

$$\begin{aligned} P := \int _{0}^{\infty }p e^{-m s} {\mathrm{d}}s = \frac{p}{m}. \end{aligned}$$

For more details, see Hilberink and Rogers [28] and Kyprianou and Surya [37].

Let \((N^{\lambda }_{t})_{t \geq 0}\) be an independent Poisson process with rate \(\lambda > 0\) and \(\mathcal{T} := (T_{n}^{\lambda })_{n \geq 1}\) its jump times. Suppose the bankruptcy is triggered at the first time of \(\mathcal{T}\) the asset value process \((V_{t})_{t \geq 0}\) goes below a given level \(V_{B} > 0\), i.e., at

$$\begin{aligned} T_{V_{B}}^{-} := \inf \left \{ S \in \mathcal{T}: V_{S} < V_{B} \right \} \end{aligned}$$

with the convention \(\inf \emptyset =\infty \). In our model, it is more natural to assume that the bankruptcy decision can be made at time zero. Hence, we modify the above and consider the random time

$$\begin{aligned} \overline{T}_{V_{B}}^{-} := \inf \left \{ S \in \mathcal{T} \cup \{0 \}: V_{S} < V_{B} \right \} = T_{V_{B}}^{-} \mathbf{1}_{\{V \geq V_{B} \}}. \end{aligned}$$

(i) Suppose first that \(V \geq V_{B}\) so that \(\overline{T}_{V_{B}}^{-} = T_{V_{B}}^{-}\). The debt pays a constant coupon flow at a fixed rate \(\rho > 0\), and a constant fraction \(0 <\alpha < 1\)of the asset value is lost at the bankruptcy time \(T_{V_{B}}^{-}\). In this setting, the value of the debt with a unit face value and maturity \(t>0\) becomes

$$\begin{aligned} d (V; V_{B}, t) &:= \mathbb{E}\bigg[ \int _{0}^{t \wedge T_{V_{B}}^{-} } e^{-rs} \rho {\mathrm{d}}s \bigg] + \mathbb{E}\big[ e^{-rt} \mathbf{1}_{ \{t < T_{V_{B}}^{-} \}} \big] \\ &\phantom{=::}+ \frac{1}{P} \mathbb{E}\big[ e^{-r T_{V_{B}}^{-}}V_{T_{V_{B}}^{-}} (1- \alpha ) \mathbf{1}_{\{T_{V_{B}}^{-} < t \}}\big]. \end{aligned}$$

Here, the first term is the total value of the coupon payments accumulated until maturity or bankruptcy whichever comes first; the second term is the value of the principal payment; the last term corresponds to the \(1/P\) fraction of the remaining asset value that is distributed, in the event of bankruptcy, to the bondholder of a unit face value. Integrating this, the total value of debt becomes, by (2.1) and Fubini’s theorem,

$$\begin{aligned} \mathcal{D} (V; V_{B}) &:= \int _{0}^{\infty }p e^{-m t} d (V; V_{B}, t) \mathrm{d}t \\ &\phantom{:}= \mathbb{E}\bigg[ \int _{0}^{T_{V_{B}}^{-}} e^{-(r+m)t} ( P \rho + p ) \mathrm{d}t\bigg] \\ &\phantom{=::}+ \mathbb{E}\big[ e^{-(r+m) T_{V_{B}}^{-}}V_{T_{V_{B}}^{-}} (1- \alpha ) \mathbf{1}_{\{T_{V_{B}}^{-} < \infty \}}\big]. \end{aligned}$$

Regarding the value of the firm, it is assumed that there is a corporate tax rate \(\kappa > 0\) and its (full) rebate on coupon payments is gained if and only if \(V_{t} \geq V_{T}\) for some given cut-off level \(V_{T} \geq 0\) (for the case \(V_{T} = 0\), it enjoys the benefit at all times). Based on the trade-off theory (see e.g. Brealey and Myers [15, Chap. 9]), the firm value becomes the sum of the asset value and total value of tax benefits less the value of loss at bankruptcy and is given by

$$\begin{aligned} \mathcal{V}(V;V_{B}) &:= V + \mathbb{E}\bigg[ \int _{0}^{T_{V_{B}}^{-} } e^{-rt} \mathbf{1}_{\{V_{t} \geq V_{T} \}} P \kappa \rho {\mathrm{d}}t \bigg] - \alpha \mathbb{E}\big[ e^{-r T_{V_{B}}^{-}}V_{T_{V_{B}}^{-}} \mathbf{1}_{\{T_{V_{B}}^{-} < \infty \}} \big]. \end{aligned}$$

(ii) Suppose now \(V< V_{B}\) so that \(\overline{T}_{V_{B}}^{-} = 0\). Then by setting \(T_{V_{B}}^{-}=0\) in the computations in (i), we obtain

$$\begin{aligned} \mathcal{D} (V; V_{B}) = \mathcal{V} (V; V_{B}) = (1-\alpha ) V. \end{aligned}$$

The problem is to find an optimal bankruptcy level \(V_{B} \geq 0\) that maximises the equity value

$$\begin{aligned} \mathcal{E}(V;V_{B}) :=\mathcal{V}(V;V_{B}) - \mathcal{D} (V; V_{B}), \end{aligned}$$

subject to the limited liability constraint

$$\begin{aligned} \mathcal{E}(V;V_{B}) \geq 0, \qquad V \geq V_{B}, \end{aligned}$$

if such a level exists. Here, \(V_{B} = 0\) means that it is never optimal to go bankrupt with the limited liability constraint satisfied for all \(V >0\). Note that when \(V < V_{B}\), then (2.3) gives \(\mathcal{E}(V;V_{B}) = 0\).

Computation of the equity value

Suppose from now on that \((X_{t})_{t \geq 0}\)is a spectrally negative Lévy process, that is, a Lévy process without positive jumps. We denote by

$$\begin{aligned} \psi (\theta ) := \log \mathbb{E}[{\mathrm{e}}^{\theta X_{1}} ], \qquad \theta \ge 0, \end{aligned}$$

its Laplace exponent with the right inverse

$$\begin{aligned} \Phi (q) := \sup \{ s \geq 0: \psi (s) = q\}, \qquad q \geq 0. \end{aligned}$$

Scale functions

The starting point of the whole analysis is introducing the so-called \(q\)-scale function \(W^{(q)}(x)\), with \(q\geq 0\) and \(x\in \mathbb{R}\). It features invariably in almost all known fluctuation identities of spectrally negative Lévy processes; see Zolotarev [56] and Takács [55, Part 4] for the origin of this function. See also Kuznetsov et al. [35] and Kyprianou and Surya [37] for a detailed review.

Fix \(q \geq 0\). The \(q\)-scale function \(W^{({q})}\) is the mapping from ℝ to \([0, \infty )\) that takes value zero on the negative half-line, while on the positive half-line it is a continuous and strictly increasing function with the Laplace transform

$$\begin{aligned} \begin{aligned} \int _{0}^{\infty }\mathrm{e}^{-\theta x} W^{({q})}(x) \mathrm{d}x &= \frac{1}{\psi (\theta )-q}, \qquad \theta > \Phi ({q}). \end{aligned} \end{aligned}$$

Define also the second scale function

$$\begin{aligned} Z^{({q})}(x; \theta ) &:=e^{\theta x} \bigg( 1 + \big(q- \psi ( \theta )\big) \int _{0}^{x} e^{-\theta z} W^{(q)}(z) \mathrm{d}z \bigg), \qquad x \in \mathbb{R}, \theta \geq 0. \end{aligned}$$

In particular, for \(x \in \mathbb{R}\), we let \(Z^{(q)}(x) :=Z^{(q)}(x; 0)\), and for \(\lambda > 0\),

$$\begin{aligned} \begin{aligned} Z^{(q)}\big(x; \Phi (q+\lambda )\big) &=e^{\Phi (q+\lambda ) x} \bigg( 1 -\lambda \int _{0}^{x} e^{-\Phi (q+\lambda ) z} W^{(q)}(z) { \mathrm{d}}z \bigg). \end{aligned} \end{aligned}$$

In the next section, we shall see that the equity value (2.4) can be written in terms of the scale functions \(W^{(q)}\) and \(Z^{(q)}\).

Related fluctuation identities

For \(y \in \mathbb{R}\), let \(\mathbb{P}_{y}\) be the conditional probability under which the initial value of the spectrally negative Lévy process is \(X_{0} = y\).

Following equation (4.5) in [37] (see also Emery [25] and Avram et al. [8, Eq. (3.19)]), the joint Laplace transform of the first passage time

$$ \tau _{0}^{-}:= \inf \{t\geq 0: X_{t}< 0\} $$

and \(X_{\tau _{0}^{-}}\) is given by the identity

$$\begin{aligned} H^{(q)}(y; \theta ) := \mathbb{E}_{y} \big[ e^{-q \tau _{0}^{-} + \theta X_{\tau _{0}^{-}}} \mathbf{1}_{\{\tau _{0}^{-}< \infty \}} \big] =Z^{({q})}(y;\theta )-\frac{\psi (\theta )-q}{\theta -\Phi (q)}W^{({q})}(y), \end{aligned}$$

where \(y\in \mathbb{R}\), \(\theta \geq 0\) and \(q \geq 0\). Similar results have been obtained for the Poisson observation case. Recall that \(\mathcal{T} :=(T_{n}^{\lambda })_{n \geq 1}\) is the set of jump times of an independent Poisson process. We define

$$\begin{aligned} \tilde{T}_{z}^{-} := \inf \{ S \in \mathcal{T} : X_{S} < z \}, \qquad z \in \mathbb{R}. \end{aligned}$$

By equation (14) of Theorem 3.1 in Albrecher et al. [2], for \(\theta \geq 0\) and \(y \in \mathbb{R}\),

$$\begin{aligned} &J^{(q, \lambda )}(y; \theta ) \\ & := \mathbb{E}_{y}\Big[ e^{-q \tilde{T}_{0}^{-} + \theta X_{ \tilde{T}_{0}^{-}}} \mathbf{1}_{\{\tilde{T}_{0}^{-}< \infty \}} \Big] \\ &\phantom{:}=\frac{\lambda }{\lambda +{q}-\psi (\theta )}\bigg(Z^{({q})}(y;\theta )-Z^{({q})}(y; \Phi ({q}+\lambda ))\frac{\psi (\theta )-{q}}{\lambda } \frac{\Phi ({q}+\lambda )-\Phi ({q})}{\theta -\Phi ({q})}\bigg) \\ &\phantom{:}=\bigg(1-\frac{\psi (\theta )-q}{\theta -\Phi (q)} \frac{\Phi (\lambda +q)-\theta }{\lambda +q-\psi (\theta )}\bigg) Z^{(q)}(y; \theta ) \\ &\phantom{=::}-\frac{\psi (\theta )-q}{\theta -\Phi (q)} \frac{\Phi (\lambda +q)-\Phi (q)}{\lambda +q-\psi (\theta )}\Big(Z^{(q)} \big(y;\Phi (\lambda +q)\big) -Z^{(q)}(y;\theta )\Big). \end{aligned}$$

Remark 3.1

1) We have

$$\begin{aligned} \begin{aligned} J^{(q, \lambda )}(0; 1) &=\frac{\lambda }{\lambda +{q}-\psi (1)} - \frac{\psi (1)-{q}}{\lambda +{q}-\psi (1)} \frac{\Phi ({q}+\lambda )-\Phi ({q})}{1-\Phi ({q})} \\ &=1-\frac{\psi (1)-{q}}{\lambda +{q}-\psi (1)} \frac{\Phi ({q}+\lambda )-1}{1-\Phi ({q})} > 0, \\ J^{(q, \lambda )}(0; 0) &=\frac{\lambda }{\lambda +{q}} - \frac{{q}}{\lambda +{q}} \frac{\Phi ({q}+\lambda )-\Phi ({q})}{\Phi ({q})} =1- \frac{{q}}{\lambda +{q}} \frac{\Phi ({q}+\lambda )}{\Phi ({q})} > 0, \end{aligned} \end{aligned}$$

where the positivity holds by the probabilistic expression of \(J^{(q,\lambda )}\) as in (3.7).

2) We have

$$\begin{aligned} J^{(q, \lambda )}(y; \theta ) < 1, \qquad q > 0, \theta \geq 0, y \in \mathbb{R}. \end{aligned}$$

To see this, by the memoryless property of the exponential distribution, we can write, for some independent exponential random variable \(\mathbf{e}_{\lambda }\), the first observation time at which \(X\) is below zero as \(\tau _{0}^{-} + \mathbf{e}_{\lambda }\), and hence \(\tilde{T}_{0}^{-}\) is bounded from below by an exponential random variable. In addition, we must have \(X_{\tilde{T}_{0}^{-}} \leq 0\)\(\mathbb{P}_{y}\)-a.s. and hence we have (3.8).

In order to write the equity value, we obtain an expression for

$$\begin{aligned} \Lambda ^{(r,\lambda )}(y,z) &:= \mathbb{E}_{y}\bigg[ \int _{0}^{ \tilde{T}_{z}^{-}} e^{-rt}\mathbf{1}_{\{X_{t} \geq \log V_{T}\}} { \mathrm{d}}t \bigg], \qquad y, z \in \mathbb{R}. \end{aligned}$$

In Appendix B, we obtain the resolvent measure killed at \(\tilde{T}_{z}^{-}\) and the following result as a corollary.

Proposition 3.2

Fix \(y, z \in \mathbb{R}\). For \(V_{T} > 0\), we have

$$\begin{aligned} \Lambda ^{(r,\lambda )}(y,z) & = Z^{(r)}\big(y-z;\Phi (r+\lambda ) \big)\frac{\Phi (r+\lambda )- \Phi (r)}{\lambda } \\ &\phantom{=:} \times \bigg( \frac{1}{\Phi (r)} Z^{(r+\lambda )}\big(z-\log V_{T}; \Phi (r)\big) - \frac{\lambda }{\Phi (r)} \overline{W}^{(r+\lambda )}(z- \log V_{T}) \bigg) \\ &\phantom{=:}- \overline{W}^{(r+\lambda )}(y- \log V_{T}) \mathbf{1}_{\{z > \log V_{T} \}} - \overline{W}^{(r)}(y-\log V_{T}) \mathbf{1}_{\{ z \leq \log V_{T} \}} \\ &\phantom{=:}+\lambda \mathbf{1}_{\{ z > \log V_{T}\}} \int _{0}^{y-z}W^{(r)}(y-z-u) \overline{W}^{(r+\lambda )}(u+z-\log V_{T}) \mathrm{d}u, \end{aligned}$$

where \(\overline{W}^{(q)}(y) := \int _{0}^{y} W^{(q)}(u) \mathrm{d}u\)for all \(q > 0\)and \(y \in \mathbb{R}\). For \(V_{T} = 0\), we have \(\Lambda ^{(r,\lambda )}(y,z)=(1-J^{(r,\lambda )}(y-z;0))/r\).

Expression for the equity value in terms of the scale function

Using the identities in Sect. 3.2, the equity value (2.4) can be written as follows. Here, we focus on the case \(V_{B} > 0\). The case \(V_{B} = 0\) (for which, as we shall see, only the case \(V_{T} = 0\) needs to be considered) is given later in (4.4).

First, (3.7) gives, for \(q = r\) and \(q = r+m\),

$$\begin{aligned} \mathbb{E}\big[ e^{-q T_{V_{B}}^{-}}V_{T_{V_{B}}^{-}} \mathbf{1}_{\{T_{V_{B}}^{-} < \infty \}} \big] &= V_{B} J^{(q, \lambda )} \bigg(\log \frac{V}{V_{B}}; 1 \bigg), \\ \mathbb{E}\big[ e^{-q T_{V_{B}}^{-}} \mathbf{1}_{\{T_{V_{B}}^{-} < \infty \}} \big] &= J^{(q, \lambda )} \bigg(\log \frac{V}{V_{B}}; 0 \bigg). \end{aligned}$$

In addition, by (3.9),

$$\begin{aligned} \mathbb{E}\bigg[ \int _{0}^{T_{V_{B}}^{-} } e^{-rt} \mathbf{1}_{\{V_{t} \geq V_{T} \}} {\mathrm{d}}t\bigg] = \Lambda ^{(r,\lambda )} (\log V, \log V_{B}). \end{aligned}$$

Hence we can write

$$\begin{aligned} \mathcal{D} (V; V_{B}) &= \frac{P \rho + p}{r+m} \bigg(1- J^{(r+m, \lambda )}\Big(\log \frac{V}{V_{B}};0 \Big) \bigg) \\ &\phantom{=:}+ (1-\alpha ) V_{B} J^{(r+m, \lambda )} \bigg(\log \frac{V}{V_{B}}; 1 \bigg), \\ \mathcal{V}(V;V_{B}) &= V + P \kappa \rho \Lambda ^{(r,\lambda )}( \log V, \log V_{B}) - \alpha V_{B} J^{(r, \lambda )}\bigg(\log \frac{V}{V_{B}}; 1 \bigg), \end{aligned}$$

and therefore, by taking their difference, the equity value is

$$\begin{aligned} \mathcal{E}(V;V_{B}) &= V + P \kappa \rho \Lambda ^{(r,\lambda )}( \log V, \log V_{B}) - \alpha V_{B} J^{(r, \lambda )}\bigg(\log \frac{V}{V_{B}}; 1\bigg) \\ &\phantom{=:}- \frac{P \rho + p}{r+m} \bigg(1- J^{(r+m, \lambda )}\Big(\log \frac{V}{V_{B}};0 \Big) \bigg) \\ &\phantom{=:}- (1-\alpha ) V_{B} J^{(r+m, \lambda )}\bigg(\log \frac{V}{V_{B}}; 1 \bigg). \end{aligned}$$

Optimal barrier

Having identified the equity value \(\mathcal{E}(V;V_{B})\) in (3.11), we are ready to find the optimal barrier \(V_{B}^{*}\) that maximises it. Our objective in this paper is to show that the optimal barrier is \(V_{B}^{*}\) such that

$$\begin{aligned} \mathcal{E}(V_{B}^{*};V_{B}^{*})=0, \end{aligned}$$

if it exists, where by (3.11) and Remark 3.1, 1), for \(V_{B} > 0\),

$$\begin{aligned} \mathcal{E}(V_{B};V_{B}) &= V_{B} + P \kappa \rho \Lambda ^{(r, \lambda )}(\log V_{B}, \log V_{B})- \alpha V_{B} J^{(r, \lambda )}(0; 1) \\ &\phantom{=:} - \frac{P \rho + p}{r+m} \big(1- J^{(r+m, \lambda )}(0;0) \big) - (1- \alpha ) V_{B} J^{(r+m, \lambda )}(0; 1) \\ &= V_{B} \big(1 - \alpha J^{(r, \lambda )}(0; 1) - (1-\alpha ) J^{(r+m, \lambda )}(0; 1)\big) \\ & \phantom{=:} + P \kappa \rho \Lambda ^{(r,\lambda )}(\log V_{B}, \log V_{B}) - \frac{P \rho + p}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)}. \end{aligned}$$


We first exhibit a condition for the existence of \(V_{B}^{*}\) satisfying (4.1). To this end, we show the following result; the proof is given in Appendix C.1.

Lemma 4.1

The mapping \(z \mapsto \Lambda ^{(r,\lambda )}(z,z)\)is nondecreasing onwith the limit

$$\begin{aligned} \lim _{z \downarrow -\infty }\Lambda ^{(r,\lambda )}(z,z) = \textstyle\begin{cases} 0 & \quad \textit{if } V_{T} > 0, \\ \frac{1}{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)} &\quad \textit{if } V_{T} = 0. \end{cases}\displaystyle \end{aligned}$$

This lemma leads to the following proposition. For numerical illustration, see Fig. 2.

Fig. 2

Plots of \(V_{B} \mapsto \mathcal{E}(V_{B};V_{B})\) for \(V_{T} = 0,10,20,\ldots , 100\). Solid lines are for the case \(V_{T}=0\) and dotted lines for the other cases. The points at \(V_{B}^{*}\) are indicated by circles. The left plot is based on the parameter set in Case B in Sect. 6 (except \(V_{T}\)), and achieves \(V_{B}^{*} > 0\) for all cases. The right plot is based on the same parameters except that we set \(\kappa = 0.9999\), \(m = 10\), \(\rho = 0.2\) and \(\lambda = 0.1\) to achieve \(V_{B}^{*} = 0\) when \(V_{T} = 0\)

Proposition 4.2

The mapping \(V_{B} \mapsto \mathcal{E}(V_{B};V_{B})\) is strictly increasing on \((0, \infty )\) with the limits

$$\begin{aligned} \lim _{V_{B} \downarrow 0 }\mathcal{E}(V_{B};V_{B}) &= \textstyle\begin{cases} - \frac{P \rho + p}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} &\quad \textit{if } V_{T} > 0, \\ \frac{P \kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}- \frac{P \rho + p}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} &\quad \textit{if } V_{T} = 0, \end{cases}\displaystyle \\ \lim _{V_{B} \uparrow \infty }\mathcal{E}(V_{B};V_{B}) &= \infty . \end{aligned}$$


From Remark 3.1, 2), we have \(1 - \alpha J^{(r, \lambda )}(0; 1) - (1-\alpha ) J^{(r+m, \lambda )}(0; 1) > 0\). By this, Lemma 4.1 and because \(z \mapsto \Lambda ^{(r,\lambda )}(z,z)\) is nondecreasing and bounded, the claim is immediate in view of the second equality in (4.2). □

Now by Proposition 4.2, we define the candidate optimal threshold \(V_{B}^{*}\) formally as follows:

1) If \(V_{T} > 0\) or if \(V_{T}= 0\) with \(\frac{P \kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}- \frac{P \rho + p}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} < 0\), we set \(V_{B}^{*}>0\) such that \(\mathcal{E}(V_{B}^{*}; V_{B}^{*}) = 0\), whose existence and uniqueness hold by Proposition 4.2.

2) If \(V_{T}= 0\) with

$$ \frac{P \kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}- \frac{P \rho + p}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} \geq 0, $$

we set \(V_{B}^{*} =0\).

The debt/firm/equity values for the case \(V_{B}^{*} >0\) can be computed by (3.10) and (3.11). For the case \(V_{B}^{*} =0\) where necessarily \(V_{T}=0\), we have, for all \(V > 0\),

$$\begin{aligned} \mathcal{D} (V; 0)&=\mathbb{E}\bigg[ \int _{0}^{\infty } e^{-(r+m)t} ( P \rho + p ) \mathrm{d}t\bigg]=\frac{P \rho + p}{r+m}, \\ \mathcal{V}(V;0) &= V + \mathbb{E}\bigg[ \int _{0}^{\infty } e^{-rt} P \kappa \rho {\mathrm{d}}t\bigg]=V+ \frac{P \kappa \rho }{r} \end{aligned}$$

and therefore

$$\begin{aligned} \mathcal{E}(V;0)=V+ \frac{P \kappa \rho }{r}-\frac{P \rho + p}{r+m}. \end{aligned}$$


In the rest of this section, we show the following one of our main results.

Theorem 4.3

The barrier \(V_{B}^{*}\)is optimal for the problem of maximising (2.4) subject to (2.5).

To prove the optimality, it is sufficient to show the following:

1) If \(V_{B}^{*} > 0\), then every threshold \(V_{B} < V_{B}^{*}\) violates the limited liability constraint (2.5).

2) \(V_{B}^{*}\) attains a higher equity value than any \(V_{B} > V_{B}^{*}\) does.

3) \(V_{B}^{*}\) is feasible.

Proposition 4.4

Suppose \(V_{B}^{*} > 0\). For \(V_{B} < V_{B}^{*}\), the limited liability constraint (2.5) is not satisfied.


By the (strict) monotonicity in Proposition 4.2 and because \(\mathcal{E}(V_{B}^{*}; V_{B}^{*}) =0\) (given that \(V_{B}^{*} > 0\)), we have \(\mathcal{E}(V_{B} ;V_{B}) < 0\) for \(V_{B} < V_{B}^{*}\). □

The proof of the following result is given in Appendix C.2.

Proposition 4.5

For \(V > V_{B} > 0\), we have

$$\begin{aligned} \frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}) &=- \big(\Phi (r+m+ \lambda )-\Phi (r+m) \big) \\ &\phantom{=-} \times H^{(r+m)}\bigg(\log \frac{V}{V_{B}}; \Phi (r+m+\lambda ) \bigg) \frac{L(\log V,\log V_{B})}{V_{B}}, \end{aligned}$$

where \(H^{(r+m)}\)is as in (3.5) and for \(x,z \in \mathbb{R}\),

$$\begin{aligned} L(x,z) &:= \frac{H^{(r)}(x-z; \Phi (r+\lambda ))}{H^{(r+m)}(x-z; \Phi (r+m+\lambda ))} \frac{\Phi (r+\lambda )-\Phi (r)}{\Phi (r+m+\lambda )-\Phi (r+m)} \\ &\phantom{=::}\times \bigg(\alpha \big(1-J^{(r, \lambda )}(0;1)\big)e^{z} \\ &\phantom{=:::\qquad }+P \kappa \rho \frac{\Phi (r+\lambda )- \Phi (r)}{\lambda }\int _{- \infty }^{z-\log V_{T}} H^{(r+\lambda )}\big(y; \Phi (r)\big)\mathrm{d}y\bigg) \\ &\phantom{=::}+(1-\alpha )\big(1-J^{(r+m, \lambda )}(0;1)\big) e^{z}- \frac{P \rho + p}{r+m}\big(1-J^{(r+m, \lambda )}(0;0)\big). \end{aligned}$$

The proofs of the following results are given in Appendices C.3 and C.4.

Proposition 4.6

Suppose \(V_{B} > V_{B}^{*} \geq 0\). We have \(\frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}) < 0\)for \(V > V_{B}\). Hence \(\mathcal{E}(V; V_{B}) < \mathcal{E}(V; V_{B}^{*})\)for all \(V > V_{B}\).

Proposition 4.7

For \(V > V_{B} > 0\), we have

$$\begin{aligned} \frac{\partial }{\partial V} \mathcal{E}(V;V_{B}) &=1- \frac{V_{B}}{V} \bigg( \frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}) +\alpha J^{(r, \lambda )}\Big(\log \frac{V}{V_{B}};1 \Big) \\ &\phantom{=::}\qquad \qquad \quad + (1-\alpha ) J^{(r+m, \lambda )}\Big(\log \frac{V}{V_{B}};1\Big) \bigg) \\ &\phantom{=:}+ \frac{P \kappa \rho }{V} R^{(r,\lambda )}\bigg(\log \frac{V}{V_{B}}, \log \frac{V_{T}}{V_{B}} \bigg), \end{aligned}$$

where \(R^{(r,\lambda )}\)is the resolvent density given in (B.2).

Proposition 4.8

We have \(\mathcal{E}(V;V_{B}^{*})\geq 0\)for all \(V\geq V_{B}^{*}\)when \(V_{B}^{*} > 0\), and for all \(V > 0\)when \(V_{B}^{*} = 0\). In other words, \(V_{B}^{*}\)is feasible.


Suppose first that \(V_{B}^{*}>0\). Because \(R^{(r,\lambda )}\) is the resolvent density, it is nonnegative. By this together with Propositions 4.6 and 4.7, for \(V> V_{B}^{*}>0\),

$$\begin{aligned} \frac{\partial }{\partial V} \mathcal{E}(V;V_{B}^{*})&=1- \frac{V_{B}^{*}}{V} \frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}^{*})- \alpha \frac{V_{B}^{*}}{V} J^{(r, \lambda )}\left (\log \frac{V}{V_{B}^{*}};1 \right ) \\ &\phantom{=:}-(1-\alpha )\frac{V_{B}^{*}}{V}J^{(r+m, \lambda )} \left (\log \frac{V}{V_{B}^{*}};1 \right ) \\ &\phantom{=:}+ \frac{P \kappa \rho }{V} R^{(r,\lambda )} \left (\log \frac{V}{V_{B}^{*}},\log \frac{V_{T}}{V_{B}^{*}} \right ) \\ &\geq 1- \frac{V_{B}^{*}}{V} \left ( \alpha J^{(r, \lambda )}\Big( \log \frac{V}{V_{B}^{*}};1 \Big) +(1-\alpha ) J^{(r+m, \lambda )} \Big(\log \frac{V}{V_{B}^{*}};1 \Big) \right ) \\ &\geq 1 - \frac{V_{B}^{*}}{V} \geq 0, \end{aligned}$$

where the second inequality holds by Remark 3.1, 2). Applying this and the fact that \(\mathcal{E}(V_{B}^{*};V_{B}^{*})= 0\) when \(V_{B}^{*} > 0\), the claim is immediate.

For the case \(V_{B}^{*}=0\), recall that necessarily \(V_{T}=0\), and hence (4.4) gives

$$ \frac{\partial }{\partial V} \mathcal{E}(V;0)=1>0.$$

Moreover, by Remark 3.1, 1) and because \(q \mapsto J^{(q, \lambda )}(0;0)\) is nonincreasing in view of its probabilistic expression, for \(m>0\),

$$\begin{aligned} \frac{{r}}{\lambda +{r}} \frac{\Phi ({r}+\lambda )}{\Phi ({r})}&=1-J^{(r, \lambda )}(0;0) \\ & \leq 1- J^{(r+m, \lambda )}(0;0)=\frac{{r+m}}{\lambda +{r}+m} \frac{\Phi ({r}+\lambda +m)}{\Phi ({r+m})}. \end{aligned}$$

By this and recalling (4.3), we have that

$$\begin{aligned} \bigg(\frac{P \kappa \rho }{r}-\frac{P \rho + p}{r+m}\bigg) \frac{{r+m}}{\lambda +{r}+m} \frac{\Phi ({r}+\lambda +m)}{\Phi ({r+m})} &\geq \frac{P \kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)} \\ &\phantom{=:}-\frac{P \rho + p}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} \\ & \geq 0. \end{aligned}$$

Hence \(\frac{P \kappa \rho }{r}-\frac{P \rho + p}{r+m} \geq 0\) and therefore

$$\begin{aligned} \lim _{V \downarrow 0}\mathcal{E}(V;0)=\frac{P \kappa \rho }{r}- \frac{ P \rho + p}{r+m}\geq 0. \end{aligned}$$

Using (4.6) together with (4.7) completes the proof. □

Proof of Theorem 4.3

By Propositions 4.4, 4.6 and 4.8, the proof is complete. □

Remark 4.9

Intuitively, as \(\lambda \rightarrow \infty \), the optimal barrier is expected to converge to that in the classical case as in Kyprianou and Surya [37]. In order to confirm this assertion, we provide the following result; its proof is deferred to Appendix C.5.

Lemma 4.10

Suppose \(V_{T} > 0\)and let \(V_{B}\geq 0\)be fixed. We have

$$\begin{aligned} \lim _{\lambda \to \infty }\frac{\lambda +r+m }{\Phi (\lambda +r+m)} \mathcal{E}(V_{B};V_{B}) &= V_{B} \bigg( \alpha \frac{\psi (1)-r}{1-\Phi (r)}+(1-\alpha ) \frac{\psi (1)-(r+m)}{1-\Phi (r+m)} \bigg) \\ &\phantom{=:}+ \frac{P \kappa \rho }{\Phi (r)}\bigg( \Big(\frac{V_{B}}{V_{T}} \Big)^{\Phi (r)}\wedge 1 \bigg) - \frac{P \rho + p}{\Phi (r+m)}. \end{aligned}$$

This is consistent with the identity (3.26) in [37], where the optimal bankruptcy level is such that the right-hand side of (4.8) vanishes.

Two-stage problem

We now obtain the optimal leverage by solving the two-stage problem as studied by Chen and Kou [19], Leland [38] and Leland and Toft [39], where the final goal is to choose \(P\) that maximises the firm’s value \(\mathcal{V}\). For fixed \(V > 0\), the problem is formulated as

$$\begin{aligned} \max _{P} \mathcal{V}\big(V; V_{B}^{*}(P), P\big) \end{aligned}$$

where we emphasise the dependence of \(\mathcal{V}\) and \(V_{B}^{*}\) on \(P\).

In this two-stage problem, it is worth investigating the shape of \(\mathcal{V}(V; V_{B}^{*}(P), P)\) with respect to \(P\) to confirm whether it has a unique maximiser. Chen and Kou [19] verified the concavity in the continuous observation case with a double jump-diffusion as the underlying model and the assumption that \(V_{T}=0\).

In this section, we show in the periodic observation setting the concavity for the case when \(V_{T}=0\) and the following assumption is satisfied.

Assumption 5.1

The Lévy measure \(\overline{\Pi }\)of the dual process \(-X\)has a completely monotone density, i.e., \(\overline{\Pi }\)has a density \(\pi \)whose \(n\)th derivative \(\pi ^{(n)}\)exists for all \(n \geq 1\)and satisfies

$$ (-1)^{n} \pi ^{(n)} (x) \geq 0, \qquad x > 0. $$

Important examples satisfying Assumption 5.1 include (the spectrally negative versions of) the hyperexponential jump-diffusion (as a generalisation of [19]), the variance gamma process (Madan and Seneta [44]), the CGMY process (Carr et al. [18]), as well as meromorphic Lévy processes (Kuznetsov et al. [34]).

To show this claim, we first show the following property.

Lemma 5.2

Under Assumption 5.1, the mapping \(x\mapsto H^{(r)}(x;\Phi (r+\lambda ))\)is decreasing.


For the completely monotone case, it is known from Loeffen [41, Theorem 2] that the scale function admits the form

$$ W^{(r)}(x) = \Phi '(r) e^{\Phi (r) x} - \int _{0}^{\infty }e^{-xt} \mu ^{(r)} (\mathrm{d}t), \qquad x \geq 0, $$

for some finite measure \(\mu ^{(r)}\). Substituting this and using Fubini’s theorem, we get

$$\begin{aligned} &Z^{({r})}\big(x; \Phi (r+\lambda ) \big) \\ &= e^{\Phi (r+\lambda ) x} \left ( 1 -\lambda \int _{0}^{x} e^{-\Phi (r+ \lambda ) z} \Big(\Phi '(r) e^{\Phi (r) z} - \int _{0}^{\infty }e^{- zt} \mu ^{(r)} (\mathrm{d}t)\Big) \mathrm{d}z \right ) \\ &= e^{\Phi (r+\lambda ) x} \bigg( 1 -\lambda \Big( \Phi '(r) \frac{1-e^{-(\Phi (r+\lambda )-\Phi (r)) x} }{\Phi (r+\lambda )-\Phi (r)} \\ &\phantom{=::}\qquad \qquad \quad - \int _{0}^{\infty }\int _{0}^{x} e^{- z(t+\Phi (r+ \lambda ))} {\mathrm{d}}z \mu ^{(r)} (\mathrm{d}t) \Big) \bigg) \\ &= e^{\Phi (r+\lambda ) x} -\lambda \bigg(\Phi '(r) \frac{ e^{\Phi (r+\lambda ) x} -e^{\Phi (r) x} }{\Phi (r+\lambda )-\Phi (r)} - \int _{0}^{\infty }\frac{ e^{\Phi (r+\lambda ) x} - e^{- tx}}{t + \Phi (r+\lambda )} \mu ^{(r)} (\mathrm{d}t) \bigg). \end{aligned}$$

Now substituting the above expressions in (3.5), we have

$$\begin{aligned} &H^{(r)}\big(x; \Phi (r+\lambda ) \big) \\ &=Z^{({r})}\big(x; \Phi (r+\lambda )\big)- \frac{\lambda }{ \Phi (r+\lambda ) -\Phi (r)}W^{({r})}(x) \\ &= e^{ \Phi (r+\lambda ) x} -\lambda \bigg( \Phi '(r) \frac{e^{ \Phi (r+\lambda ) x}-e^{\Phi (r) x} }{ \Phi (r+\lambda ) - \Phi (r) } - \int _{0}^{\infty }\frac{ e^{ \Phi (r+\lambda ) x} - e^{- xt}}{t + \Phi (r+\lambda ) } \mu ^{(r)} (\mathrm{d}t) \bigg) \\ &\phantom{=:}- \frac{\lambda }{ \Phi (r+\lambda ) -\Phi (r)} \bigg( \Phi '(r) e^{ \Phi (r) x} - \int _{0}^{\infty }e^{-tx} \mu ^{(r)} (\mathrm{d}t) \bigg) \\ &= e^{ \Phi (r+\lambda ) x}A + B(x), \end{aligned}$$


$$\begin{aligned} A &:= 1 - \frac{ \lambda \Phi '(r) }{\Phi (r+\lambda ) -\Phi (r)} + \int _{0}^{\infty }\frac{\lambda }{t + \Phi (r+\lambda ) } \mu ^{(r)} ({ \mathrm{d}}t), \\ B(x) &:= \lambda \int _{0}^{\infty }e^{- xt}\bigg( \frac{1}{ \Phi (r+\lambda ) -\Phi (r)} - \frac{1}{t + \Phi (r+\lambda ) } \bigg) \mu ^{(r)} (\mathrm{d}t). \end{aligned}$$

Because \(\lim _{x\to \infty }H^{(r)}(x; \Phi (r+\lambda ) ) =0\) in view of the probabilistic expression (3.5) and \(\lim _{x \rightarrow \infty } B(x) = 0\) by monotone convergence, we must have \(A = 0\). Hence \(H^{(r)}(x; \Phi (r+\lambda ) ) = B(x)\) and its derivative becomes

$$\begin{aligned} &\frac{\partial }{\partial x}H^{(r)}\big(x; \Phi (r+\lambda ) \big) \\ & = B'(x) \\ &=-\lambda \int _{0}^{\infty }t e^{- xt} \bigg( \frac{1}{ \Phi (r+\lambda ) -\Phi (r)} - \frac{1}{t + \Phi (r+\lambda ) } \bigg) \mu ^{(r)} (\mathrm{d}t) \\ &< 0, \end{aligned}$$

where the negativity holds because \(\Phi (r+\lambda ) > \Phi (r) > 0\) and hence the integrand is always positive. This shows the claim. □

Now suppose \(V_{T}=0\) so that

$$\mathcal{V}(V;V_{B}, P)=V+\mathbb{E}\bigg[\int _{0}^{T_{V_{B}}^{-}}e^{-rt}P \kappa \rho {\mathrm{d}}t \bigg]-\alpha \mathbb{E}\big[e^{-rT_{V_{B}}^{-}} V_{T_{V_{B}}^{-}}\mathbf{1}_{\{T_{V_{B}}^{-}< \infty \}}\big]. $$

By Proposition 3.2 and (4.2), the optimal barrier \(V_{B}^{*}(P)\) is given by the root of \(\mathcal{E}(V_{B};V_{B}, P) = 0\) for the case \(V_{B}^{*}(P) > 0\), where

$$\begin{aligned} \mathcal{E}(V_{B};V_{B}, P) &= V_{B} + \frac{P \kappa \rho }{r} \big(1- J^{(r, \lambda )}(0;0) \big) \\ &\phantom{=:}- \alpha V_{B} J^{(r, \lambda )}(0; 1) - \frac{P \rho + p}{r+m} \big(1- J^{(r+m, \lambda )}(0;0) \big) \\ &\phantom{=:} - (1-\alpha ) V_{B} J^{(r+m, \lambda )}(0; 1). \end{aligned}$$

Recall that by (4.3) and due to \(p = mP\),

$$\begin{aligned} V_{B}^{*} (P)= 0 &\quad \Longleftrightarrow \quad \lim _{V_{B} \downarrow 0}\mathcal{E}(V_{B};V_{B}, P) \geq 0 \\ & \quad \Longleftrightarrow \quad \frac{\kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}-\frac{\rho + m}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} \geq 0, \end{aligned}$$

which does not depend on the value of \(P\). Hence the criterion for \(V_{B}^{*}(P) = 0\) is irrelevant to the selection of \(P\).

1) First consider the case \(\frac{\kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}- \frac{\rho + m}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} \geq 0\) so that \(V_{B}^{*}(P) = 0\) for any choice of \(P > 0\). In this case,

$$ \mathcal{V}\big(V;V_{B}^{*}(P), P \big) = \mathcal{V}(V;0,P) = V + \frac{P \kappa \rho }{r}, $$

which is linear (and hence concave) in \(P\).

2) Suppose \(\frac{\kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}- \frac{\rho + m}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} < 0\) so that \(V_{B}^{*}(P) > 0\) is irrelevant to the selection of \(P\). Because \(p=Pm\), solving \(\mathcal{E}(V_{B};V_{B}, P) = 0\) with (5.2) gives

$$\begin{aligned} V_{B}^{*}(P) &=- \frac{ \frac{P \kappa \rho }{r} (1- J^{(r, \lambda )}(0;0) )-\frac{P \rho + p}{r+m} (1- J^{(r+m, \lambda )}(0;0) )}{ 1-\alpha J^{(r, \lambda )}(0; 1)- (1-\alpha ) J^{(r+m, \lambda )}(0; 1)} =\varepsilon P, \end{aligned}$$


$$\begin{aligned} \varepsilon := - \frac{ \frac{ \kappa \rho }{r} (1- J^{(r, \lambda )}(0;0) )-\frac{ \rho + m}{r+m} (1- J^{(r+m, \lambda )}(0;0) )}{ 1-\alpha J^{(r, \lambda )}(0; 1)- (1-\alpha ) J^{(r+m, \lambda )}(0; 1)} > 0. \end{aligned}$$

Now as in (3.10) and Proposition 3.2, the firm’s value is given by

$$\begin{aligned} &\mathcal{V}\big(V;V_{B}^{*}(P),P\big) \\ &=V+\frac{P \kappa \rho }{r} \left (1- J^{(r, \lambda )}\Big(\log \frac{V}{V_{B}^{*}(P)};0\Big) \right )-\alpha V_{B}^{*}(P) J^{(r, \lambda )}\bigg(\log \frac{V}{V_{B}^{*}(P)};1\bigg) \\ &=V+\frac{P \kappa \rho }{r} \left (1- J^{(r, \lambda )}\Big(\log \frac{V}{\varepsilon P};0\Big)\right )-\alpha \varepsilon P J^{(r, \lambda )}\bigg(\log \frac{V}{\varepsilon P};1\bigg). \end{aligned}$$

Differentiating the above expression and using Lemmas C.1 and C.2 (in Appendix C), we have

$$\begin{aligned} &\frac{\partial }{\partial P}\mathcal{V}\big(V;V_{B}^{*}(P),P\big) \\ &=\frac{\kappa \rho }{r} \left (1- J^{(r, \lambda )}\Big(\log \frac{V}{\varepsilon P};0\Big)\right ) \\ &\phantom{=:}-\frac{\kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )-\Phi (r)}{\Phi (r)}\Phi (r+\lambda )H^{(r)} \bigg(\log \frac{V}{\varepsilon P};\Phi (r+\lambda )\bigg) \\ &\phantom{=:}-\alpha \varepsilon \frac{\psi (1)-r}{\lambda +r-\psi (1)} \frac{\Phi (r+\lambda )-\Phi (r)}{1-\Phi (r)}\big(\Phi (r+\lambda )-1 \big)H^{(r)}\bigg(\log \frac{V}{\varepsilon P};\Phi (r+\lambda ) \bigg). \end{aligned}$$

Here the coefficient \(\frac{\psi (1)-r}{\lambda +r-\psi (1)} \frac{\Phi (r+\lambda )-\Phi (r)}{1-\Phi (r)}(\Phi (r+\lambda )-1)\) is positive by the convexity of \(\psi \) on \([0,\infty )\).

The mapping \(x \mapsto J^{(r, \lambda )}(x;0)=\mathbb{E}_{x} [ e^{-r\tilde{T}_{0}^{-}} \mathbf{1}_{\{\tilde{T}_{0}^{-}<\infty \}} ] = \mathbb{E}[ e^{-r \tilde{T}_{-x}^{-}}\mathbf{1}_{\{\tilde{T}_{-x}^{-}<\infty \}} ]\) is decreasing because \(\tilde{T}_{-x}^{-}\) is increasing in \(x\). On the other hand, Lemma 5.2 shows that the mapping \(x\mapsto H^{(r)}(x;\Phi (r+\lambda ))\) is decreasing as well.

Using these facts together with (5.3), we can conclude that \(\frac{\partial }{\partial P}\mathcal{V}(V;V_{B}^{*}(P),P)\) is decreasing in \(P\), and therefore that the firm’s value \(\mathcal{V}(V;V_{B}^{*}(P),P)\) is a concave function of \(P\). In summary, we have the following result.

Theorem 5.3

Suppose \(V_{T} = 0\)and Assumption 5.1is satisfied.

(1) If \(\frac{\kappa \rho }{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}- \frac{\rho + m}{\lambda +r+m} \frac{\Phi (r+m+\lambda )}{\Phi (r+m)} \geq 0\), then \(V_{B}^{*}(P) = 0\)for all \(P > 0\)and we have \(\mathcal{V}(V; V_{B}^{*}(P),P) = V + \frac{P \kappa \rho }{r}\).

(2) Otherwise, \(V_{B}^{*}(P)=\varepsilon P > 0\)for all \(P > 0\)and \(\mathcal{V}(V; V_{B}^{*}(P),P)\)is concave in \(P\)for any \(V > 0\).

Numerical examples

In this section, we confirm the analytical results obtained in the previous sections through a sequence of numerical examples. In addition, we study numerically the impact of the rate of observation \(\lambda \) on the solutions, obtain the optimal leverage by considering the two-stage problem considered in (5.1), and analyse the behaviours of credit spreads.

Throughout this section, we use \(r=7.5\%\), \(\delta =7\%\), \(\kappa = 35\%\), \(\alpha =50\%\) for the parameters of the problem as used in [28, 37, 38, 39]. Additionally, unless stated otherwise, we set \(\rho = 8.162\%\) and \(m=0.2\), which were used in [19], \(P=50\) and \(\lambda = 4\) (on average four times per year). For the tax threshold, we set

$$\begin{aligned} V_{T} = P\rho /\delta \end{aligned}$$

as used in [37] and also suggested by [28, 39]. By the choice (6.1), necessarily \(V_{T} > 0\) and hence \(V_{B}^{*} > 0\) as discussed in Sect. 4.1.

For the process \((X_{t})_{t \geq 0}\), we use a mixture of Brownian motion and a compound Poisson process with i.i.d. hyperexponential jumps, \(X_{t}=\mu t +\sigma B_{t} -\sum _{k=1}^{N_{t}}U_{k}\), \(t \geq 0\), where \((B_{t})_{t \geq 0}\) is a standard Brownian motion, \((N_{t})_{t \geq 0}\) is a Poisson process with intensity \(\gamma \) and each \(U_{k}\) takes an exponential random variable with rate \(\beta _{i} > 0\) with probability \(p_{i}\) for \(1 \leq i \leq m\) such that \(\sum _{i=1}^{m} p_{i} = 1\). Note that this process satisfies the complete monotonicity condition in Assumption 5.1. The corresponding Laplace exponent (3.1) becomes

$$\begin{aligned} \psi (s) = \mu s + \frac{1}{2} \sigma ^{2} s^{2} + \gamma \sum _{i=1}^{m} p_{i} \bigg( \frac{\beta _{i}}{\beta _{i} + s} -1\bigg), \qquad s \geq 0. \end{aligned}$$

This is a special case of a phase-type Lévy process (Asmussen et al. [4]), and its scale function has an explicit expression written as a sum of exponential functions; see e.g. Egami and Yamazaki [24] or Kuznetsov et al. [35]. In particular, we consider the following two parameter sets:

Case A (without jumps): \(\sigma = 0.2\), \(\mu = -0.015\), \(\gamma = 0\);

Case B (with jumps): \(\sigma = 0.2\), \(\mu = 0.055\), \(\gamma = 0.5\), \((p_{1}, p_{2}) = (0.9,0.1)\) and \((\beta _{1}, \beta _{2}) = (9,1)\).

Here \(\mu \) is chosen such that the martingale property \(\psi (1)=r-\delta = 0.005\) is satisfied. In Case B, the jump size \(U\) models both small and large jumps (with parameters 9 and 1) that occur with probabilities 0.9 and 0.1, respectively.


For the above parameter settings, we first confirm the optimality of the suggested barrier \(V_{B}^{*}\) that satisfies \(\mathcal{E}(V_{B}^{*};V_{B}^{*}) = 0\). Because the mapping \(V_{B} \mapsto \mathcal{E}(V_{B};V_{B})\) (given in (4.2)) is monotonically increasing (see Proposition 4.2), the value of \(V_{B}^{*}\) can be computed by classical bisection methods. The corresponding capital structure is then computed by (3.10) and (3.11).

At the top of Fig. 3, for Cases A and B, we plot \(V \mapsto \mathcal{E}(V; V_{B}^{*})\) along with \(V \mapsto \mathcal{E}(V; V_{B})\) for \(V_{B} \neq V_{B}^{*}\). Here, we confirm Theorem 4.3: the level \(V_{B}^{*}\) satisfies the limited liability constraint (2.5), and any level \(V_{B}\) lower than \(V_{B}^{*}\) violates (2.5), while for \(V_{B}\) larger than \(V_{B}^{*}\), \(\mathcal{E}(V; V_{B})\) is dominated by \(\mathcal{E}(V; V_{B}^{*})\). The corresponding debt and firm values are also plotted in Fig. 3.

Fig. 3

The equity/debt/firm values as functions of \(V\) on \((V_{B}, \infty )\) for \(V_{B}=V_{B}^{*}\) (solid) along with \(V_{B} = V_{B}^{*} \exp (\epsilon )\) (dotted) for \(\epsilon = -0.5,-0.4, \ldots , -0.1, 0.1, 0.2, \ldots , 0.5\). The values at \(V = V_{B}\) are indicated by circles for \(V_{B} = V_{B}^{*}\), whereas those for \(V_{B} < V_{B}^{*}\) (resp. \(V_{B} > V_{B}^{*}\)) are indicated by up- (resp. down-) pointing triangles

Sensitivity with respect to \(\lambda \) of the equity value

We now proceed to study the sensitivity of the optimal bankruptcy barrier and the equity value with respect to the rate of observation \(\lambda \). In the left plot of Fig. 4, we show the equity value \(\mathcal{E}(\, \cdot \, ; V_{B}^{*})\) for various values of \(\lambda \) along with the classical (continuous-observation) case as obtained in [28, 37]. We see that the optimal barrier \(V_{B}^{*}\) is decreasing in \(\lambda \) and converges to the optimal barrier, say \(\tilde{V}_{B}\), of the classical case. This confirms Remark 4.9.

Fig. 4

(Top) The equity values \(\mathcal{E}(V; V_{B}^{*})\) (dotted) for \(\lambda = 1,2,4,6,12,52,365\) along with the classical case \(\tilde{\mathcal{E}}(V; \tilde{V}_{B})\) (solid). The corresponding values at \(V = V_{B}^{*}\) are indicated by circles. (Bottom) The difference \(\mathcal{E}(V; V_{B}^{*}) - \tilde{\mathcal{E}}(V; \tilde{V}_{B})\) for the same set of \(\lambda \)-values

We also confirm the convergence of \(\mathcal{E}(V;V_{B}^{*})\) to the classical case, say \(\tilde{\mathcal{E}}(V;\tilde{V}_{B})\), for each starting value \(V\). On the other hand, monotonicity of \(\mathcal{E}(V;V_{B}^{*})\) with respect to \(\lambda \) fails. When \(V\) is small, the equity value tends to be higher for small values of \(\lambda \), but it is not necessarily so for higher values of \(V\). In order to investigate this, we show in the bottom plots of Fig. 4 the difference \(\mathcal{E}(V;V_{B}^{*})- \tilde{\mathcal{E}}(V;\tilde{V}_{B})\). We observe also the differences between Cases A and B — in Case A, a lower value of \(\lambda \) clearly achieves higher equity value when \(V\) is large whereas this is not clear in Case B.

Analysis of the bankruptcy time and the asset value at bankruptcy

While it was confirmed that the barrier level \(V_{B}^{*}\) is monotone in \(\lambda \), it is not clear how the distributions of \((T^{-}_{V_{B}^{*}}, V_{T^{-}_{V_{B}^{*}}})\) change in \(\lambda \). Here, by taking advantage of the joint Laplace transform \((q, \theta ) \mapsto J^{(q, \lambda )} (\, \cdot \, ; \theta )\) as in (3.7), we compute numerically the density and distribution of the random variables \(T^{-}_{V_{B}^{*}}\) and \(V_{T^{-}_{V_{B}^{*}}}\) for each \(\lambda \). We also obtain those in the classical case by inverting \((q, \theta ) \mapsto H^{(q)} (\, \cdot \, ; \theta )\) as in (3.5).

For Laplace inversion, we adopt the Gaver–Stehfest algorithm, whose use was suggested in Kou and Wang [31] (see also Kuznetsov [33] for its convergence results). The algorithm is easy to implement and only requires real values. While a major challenge is to handle the cases involving large numbers, our case can be handled without difficulty in the standard Matlab environment with double precision.

In our case, the scale function \(W^{(q)}\) is written in terms of a linear sum of \(e^{\Phi (q)x}\) and \(e^{-\xi _{i,q}x}\), \(1 \leq i \leq n\) (\(n=1\) in Case A and \(n=3\) in Case B), where \(\Phi (q)\) is as in (3.2) and \(-\xi _{i,q}\) are the negative roots of \(\psi (\, \cdot \,) = q\). As in the proof of Lemma 5.2, the terms for \(e^{\Phi (q) x}\) all cancel out in the Laplace transforms \(J^{(q, \lambda )}(\, \cdot \, ; \theta )\) and \(H^{(q)}( \, \cdot \, ; \theta )\). Hence the algorithm runs without the need of handling large numbers even for high values of \(q\). The same can be said about the parameter \(\theta \).

For the initial value \(V = 100\), we plot in Fig. 5 the density and distribution functions of \(T^{-}_{V_{B}^{*}}\) and in Fig. 6 those for \(V_{T^{-}_{V_{B}^{*}}}\) for the same parameter sets as used for Fig. 4 (note that the value of \(V_{B}^{*}\) depends on \(\lambda \)). For comparison, those in the classical case (computed by inverting \((q, \theta )\mapsto H^{(q)}(\log V; \theta )\)) are also plotted. It is noted that in Fig. 6, the distribution is not purely diffusive and instead the probability of the event \(V_{T^{-}_{V_{B}^{*}}}=V_{B}^{*}\) is strictly positive. In particular, for Case A, \(V_{T^{-}_{V_{B}^{*}}}=V_{B}^{*}\) a.s. At least in our examples, the distribution functions for \(T^{-}_{V_{B}^{*}}\) appear to be monotone in \(\lambda \), while they are not for \(V_{T^{-}_{V_{B}^{*}}}\).

Fig. 5

Density \(\mathbb{P}[T_{V_{B}^{*}}^{-} \in {\mathrm{d}}t]/ {\mathrm{d}}t\) and distribution \(\mathbb{P}[T_{V_{B}^{*}}^{-} \leq t]\) (indicated by dotted lines) for \(\lambda = 1,2,4,6,12,52,365\), the initial value \(V = 100\) and \(V_{B}^{*}\) determined as in Fig. 4. The classical cases are also shown by solid lines. These values are plotted against the logarithm of time

Fig. 6

Density \(\mathbb{P}[V_{T_{V_{B}^{*}}^{-}} \in {\mathrm{d}}v]/ {\mathrm{d}}v\) and distribution \(\mathbb{P}[V_{T_{V_{B}^{*}}^{-}} \leq v]\) (indicated by dotted lines) for \(\lambda = 1,2,4,6,12,52,365\), the initial value \(V = 100\) and \(V_{B}^{*}\) determined as in Fig. 4. The classical cases are also shown by solid lines, in which the distribution of the value at bankruptcy has a positive mass at the bankruptcy level

Two-stage problem

Now we consider the two-stage problem (5.1). Recall, as confirmed in Theorem 5.3, that the firm value \(\mathcal{V}(V;V_{B}^{*}(P), P)\) is concave in \(P\) for the case \(V_{T} = 0\). Here, in order to see if the concavity holds when \(V_{T} > 0\), we continue to use the tax cutoff level \(V_{T}\) from (6.1) as a function of \(P\).

For our numerical results, we set \(V = 100\) and obtain \(V_{B}^{*}\) for \(P\) running from 0 to 100 (leverage \(P/V\) running from 0 to 1). The corresponding firm and debt values are computed for each \(P\) and \(V_{B}^{*} = V_{B}^{*}(P)\), and shown in Fig. 7. For comparison, analogous results on the classical case are also plotted. Here, the concavity with respect to \(P\) is confirmed in all considered cases.

Fig. 7

The firm values (top) and debt values (bottom) as functions of the leverage \(P/V\) for the two-stage problem for \(V = 100\). The periodic cases with \(\lambda = 1,2,4,6,12,52,365\) (dotted) are indicated by dotted lines, and the classical case corresponds to the solid lines. The points at \(P^{*}/V\) are indicated by circles

Regarding the analysis with respect to \(\lambda \), at least in these examples, we observe that the firm and debt values for each \(P\) are monotone in \(\lambda \) and converge to those in the classical case. In addition, we see that the optimal face value \(P^{*}\) decreases in \(\lambda \) and converges to that in the classical case.

The term structure of credit spreads

We now move on to the analysis of the credit spread. Let \(V_{B} > 0\) be a fixed bankruptcy level. The credit spread is defined as the excess of the amount of coupon over the risk-free interest rate required to induce the investor to lend one dollar to the firm until the maturity time \(t\). To be more precise, by finding the coupon rate \(\rho ^{*}\) that makes the value of the debt \(d(V;V_{B},t)\) defined in (2.2) of unit face value equal to one, the credit spread \(\rho ^{*}-r\) is given after some rearrangement of (2.2) by

$$\begin{aligned} \mathrm{CS}_{\lambda }(t)=\frac{r}{P} \frac{\mathbb{E} [ (P-(1-\alpha )V_{T_{V_{B}^{-}}} ) e^{-r T_{V_{B}}^{-}}\mathbf{1}_{\{T_{V_{B}}^{-} \leq t\}} ]}{\mathbb{E} [1- e^{-r(t\wedge T_{V_{B}}^{-})} ]}. \end{aligned}$$

Before showing numerical results, we prove the following analytical limits. The proofs are deferred to Appendices C.6 and C.7.

Proposition 6.1

For \(V\neq V_{B}\), we have \(\lim _{t \downarrow 0} \mathrm{CS}_{\lambda }(t)=\frac{\lambda }{P} ( P-(1- \alpha )V ) \mathbf{1}_{\{V< V_{B}\}}\).

Let \(\mathrm{CS}(t)\) denote the credit spread in the classical case as described in Hilberink and Rogers [28].

Proposition 6.2

For \(V_{B} > 0\), \(V\neq V_{B}\)and \(t > 0\), we have \(\lim _{\lambda \to \infty }\mathrm{CS}_{\lambda }(t)=\mathrm{CS}(t)\).

Remark 6.3

While theoretically the credit spread converges to zero as the maturity \(t\) decreases to zero as in Proposition 6.1 when \(V > V_{B}\), we shall see below that the rate of convergence can be controlled by the selection of \(X\) and \(\lambda \) and can be made very slow as shown in Fig. 8 below.

Fig. 8

Term structure of credit spreads with respect to the logarithm of maturity for \(V = 100\). The periodic cases with \(\lambda = 1,2,4,6,12,52,365\) (dotted) are indicated by dotted lines and the classical case corresponds to the solid lines

To compute credit spreads, we follow the procedures for Fig. 6 of Hilberink and Rogers [28] (given in their Appendix B).

Fix \(V\) and \(m\). The first step is to choose, for fixed leverage \(0 \leq L \leq 1\), the face value of debt \(\hat{P} := \hat{P}(L)\) and \(\hat{\rho } = \hat{\rho }(L)\) satisfying \(\mathcal{D}(V; \hat{V}_{B}) := \mathcal{D}(V; \hat{V}_{B}; \hat{P}, \hat{\rho }) = \hat{P}\) and \(L = \hat{P}/\mathcal{V}(V; \hat{V}_{B}) := \hat{P}/\mathcal{V}(V; \hat{V}_{B}; \hat{P}, \hat{\rho })\), where \(\hat{V}_{B}\) is the optimal bankruptcy level when \(\rho = \hat{\rho }\) and \(P = \hat{P}\). For this computation, at least in our numerical experiments, the mapping \(P \mapsto P/\mathcal{V}(V; \hat{V}_{B}; P, \rho )\), for fixed \(\rho \), is monotonically increasing and hence the root \(\hat{P}(\rho )\) solving \(L = \hat{P}(\rho )/\mathcal{V}(V; \hat{V}_{B}; \hat{P}(\rho ), \rho )\) was obtained by classical bisection. In addition, \(\rho \mapsto \mathcal{D}(V; \hat{V}_{B}; \hat{P}(\rho ), \rho ) - \hat{P}(\rho )\) was also monotone and hence the desired \(\hat{P}\) and \(\hat{\rho }\) were obtained by (nested) bisection methods.

For each leverage \(L\), after \(\hat{P}\) and \(\hat{\rho }\) are computed, the second step is to obtain for each maturity \(t > 0\) the root \(\rho ^{*} = \rho ^{*}(t)\) with \(1 = d(V; \hat{V}_{B}, t) := d(V; \hat{V}_{B}, t; \rho ^{*})\), where

$$\begin{aligned} d (V; \hat{V}_{B}, t; \rho ) &:= \mathbb{E}\bigg[ \int _{0}^{t \wedge T_{\hat{V}_{B}}^{-} } e^{-rs} \rho {\mathrm{d}}s \bigg] + \mathbb{E}\big[ e^{-rt} \mathbf{1}_{\{t < T_{\hat{V}_{B}}^{-} \}} \big] \\ &\phantom{=::} + \frac{1}{\hat{P}} \mathbb{E}\big[ e^{-r T_{ \hat{V}_{B}}^{-}}V_{T_{ \hat{V}_{B}}^{-}} (1-\alpha ) \mathbf{1}_{\{T_{ \hat{V}_{B}}^{-} < t \}} \big]. \end{aligned}$$

The spread is given by \(\rho ^{*} - r\) (for each maturity \(t\)). The expectations on the right-hand side can be computed again by the Gaver–Stehfest algorithm, by inverting \(q \mapsto J^{(q, \lambda )}(\, \cdot \, ; \theta )\) as in (3.7) for \(\theta = 0, 1\). Those for the classical case can be computed by inverting \(q \mapsto H^{(q)}(\, \cdot \, ; \theta )\).

Here, we consider leverages \(L = 50,75\) again for Cases A and B. In Table 1, the computed values of \(\hat{P}\), \(\hat{\rho }\) and \(\hat{V}_{B}\) are listed for each \(\lambda = 1,2,4,6,12,52,365\) along with those for the classical case. In Fig. 8, we plot the credit spread with respect to the log maturity for each \(\lambda \). For comparison, we also plot those in the classical case. The spread appears to be monotone in \(\lambda \) and converges to that in the classical case for each maturity.

Table 1 Values of \(\hat{P}\), \(\hat{\rho }\) and \(\hat{V}_{B}\) satisfying \(L = \hat{P}/\mathcal{V}(V; \hat{V}_{B}) := \hat{P}/\mathcal{V}(V; \hat{V}_{B}; \hat{P}, \hat{\rho })\) for \(L = 50,75\) and \(\mathcal{D}(V; \hat{V}_{B}) := \mathcal{D}(V; \hat{V}_{B}; \hat{P}, \hat{\rho }) = \hat{P}\) for each \(\lambda \) (\(\lambda = \infty \) corresponds to the classical case)

Regarding the credit spread limit, while the convergence to zero has been confirmed in Proposition 6.1 for the periodic case, the rate of convergence depends significantly on the selection of \(\lambda \) and the underlying asset value process. In Case A (without negative jumps), the credit spread converges to zero quickly as the maturity decreases. On the other hand, in Case B (where the credit spread does not converge to zero as the maturity goes to zero in the continuous-observation case), the convergence to zero of the credit spread is very slow for large values of \(\lambda \), as can be seen in Fig. 8. In view of these observations, with a selection of asset values with negative jumps and the observation rate \(\lambda \), realistic short-maturity credit spread behaviours can be achieved.

Concluding remarks

We have studied an extension of the Leland–Toft optimal capital structure model where the information on the asset value is updated only at the jump times of an independent Poisson process. In settings where the asset value follows an exponential Lévy process with negative jumps, we have obtained explicitly an optimal bankruptcy strategy and the corresponding equity/debt/firm values. These analytical results have enabled us to efficiently conduct numerical experiments and further analysis of the impact of the observation rate on the optimal leverages and credit spreads.

There are various venues for future research. First, it is a natural direction to consider the case in which the asset value process contains both positive and negative jumps. Because positive jumps do not have a direct influence on the model of the default, similar results are expected, and for example the optimal barrier is likely to be given by \(V_{B}\) such that \(\mathcal{E}(V_{B};V_{B}) = 0\). While the techniques using the scale function employed in this paper cannot be directly applied to two-sided jump cases, there are several potential alternative approaches. One approach would be to add phase-type upward jumps to a spectrally negative Lévy process via fluid embedding and construct a Lévy process with two-sided jumps in terms of a Markov additive process. To do this, the phase-type jumps of the Lévy process can be substituted by linear stretches of unit slope. This procedure requires though adding a supplementary background Markov chain; see e.g. Ivanovs [29, Sect. 2.7] for details. Another approach would be to focus on a Lévy process with two-sided phase-type distributed jumps and use them to approximate a general case. This may be possible by combining the results of Asmussen et al. [4] and Albrecher et al. [2].

Second, it is important to consider the constant grace period case described in 1) of Sect. 1.1. As discussed, this paper’s results, featuring exponential grace periods, may be used to approximate the constant case when the grace period is short. However, an alternative approach is required when it is long. One potential approach would be to use Carr’s [17] randomisation method to approximate the constant period in terms of an Erlang random variable, or the sum of i.i.d. exponential random variables. As in Leung et al. [40], a recursive algorithm may be constructed to compute the required fluctuation identities.


  1. 1.

    Albrecher, H., Ivanovs, J.: Strikingly simple identities relating exit problems for Lévy processes under continuous and Poisson observations. Stoch. Process. Appl. 127, 643–656 (2017)

    MATH  Article  Google Scholar 

  2. 2.

    Albrecher, H., Ivanovs, J., Zhou, X.: Exit identities for Lévy processes observed at Poisson arrival times. Bernoulli 22, 1364–1382 (2016)

    MathSciNet  MATH  Article  Google Scholar 

  3. 3.

    Alili, L., Kyprianou, A.E.: Some remarks on first passage of Lévy processes, the American put and pasting principles. Ann. Appl. Probab. 15, 2062–2080 (2005)

    MathSciNet  MATH  Article  Google Scholar 

  4. 4.

    Asmussen, S., Avram, F., Pistorius, M.R.: Russian and American put options under exponential phase-type Lévy models. Stoch. Process. Appl. 109, 79–111 (2004)

    MATH  Article  Google Scholar 

  5. 5.

    Avanzi, B., Cheung, E.C., Wong, B., Woo, J.K.: On a periodic dividend barrier strategy in the dual model with continuous monitoring of solvency. Insur. Math. Econ. 52, 98–113 (2013)

    MathSciNet  MATH  Article  Google Scholar 

  6. 6.

    Avanzi, B., Tu, V., Wong, B.: On optimal periodic dividend strategies in the dual model with diffusion. Insur. Math. Econ. 55, 210–224 (2014)

    MathSciNet  MATH  Article  Google Scholar 

  7. 7.

    Avram, F., Kyprianou, A.E., Pistorius, M.R.: Exit problems for spectrally negative Lévy processes and applications to (Canadized) Russian options. Ann. Appl. Probab. 14, 215–238 (2004)

    MathSciNet  MATH  Article  Google Scholar 

  8. 8.

    Avram, F., Palmowski, Z., Pistorius, M.: On the optimal dividend problem for a spectrally negative Lévy process. Ann. Appl. Probab. 17, 156–180 (2007)

    MathSciNet  MATH  Article  Google Scholar 

  9. 9.

    Avram, F., Pérez, J.L., Yamazaki, K.: Spectrally negative Lévy processes with Parisian reflection below and classical reflection above. Stoch. Process. Appl. 128, 255–290 (2018)

    MATH  Article  Google Scholar 

  10. 10.

    Baurdoux, E.J., Pardo, J.C., Pérez, J.L., Renaud, J.F.: Gerber–Shiu distribution at Parisian ruin for Lévy insurance risk processes. J. Appl. Probab. 53, 572–584 (2016)

    MathSciNet  MATH  Article  Google Scholar 

  11. 11.

    Bertoin, J.: Lévy Processes. Cambridge University Press, Cambridge (1996)

    MATH  Google Scholar 

  12. 12.

    Bielecki, T.R., Rutkowski, M.: Credit Risk: Modeling, Valuation and Hedging. Springer, Berlin (2013)

    MATH  Google Scholar 

  13. 13.

    Billingsley, P.: Convergence of Probability Measures, 2nd edn. Wiley, New York (1999)

    MATH  Book  Google Scholar 

  14. 14.

    Black, F., Cox, J.: Valuing corporate securities: some effects of bond indenture provisions. J. Finance 31, 351–367 (1976)

    Article  Google Scholar 

  15. 15.

    Brealey, R.A., Myers, S.C.: Principles of Corporate Finance. McGraw-Hill, New York (2001)

    Google Scholar 

  16. 16.

    Broadie, M., Chernov, M., Sundaresan, S.: Optimal debt and equity values in the presence of Chap. 7 and Chap. 11. J. Finance 62, 1341–1377 (2007)

    Article  Google Scholar 

  17. 17.

    Carr, P.: Randomization and the American put. Rev. Financ. Stud. 11, 597–626 (1998)

    MATH  Article  Google Scholar 

  18. 18.

    Carr, P., Geman, H., Madan, D.B., Yor, M.: The fine structure of asset returns: an empirical investigation. J. Bus. 75, 305–332 (2002)

    Article  Google Scholar 

  19. 19.

    Chen, N., Kou, S.G.: Credit spreads, optimal capital structure, and implied volatility with endogenous default and jump risk. Math. Finance 19, 343–378 (2009)

    MathSciNet  MATH  Article  Google Scholar 

  20. 20.

    Chesney, M., Jeanblanc-Picqué, M., Yor, M.: Brownian excursions and Parisian barrier options. Adv. Appl. Probab. 29, 165–184 (1997)

    MathSciNet  MATH  Article  Google Scholar 

  21. 21.

    Cont, R., Tankov, P.: Financial Modelling with Jump Processes. Chapman & Hall, London (2003)

    MATH  Google Scholar 

  22. 22.

    Duffie, D., Lando, D.: Term structure of credit spreads with incomplete accounting information. Econometrica 69, 633–664 (2001)

    MathSciNet  MATH  Article  Google Scholar 

  23. 23.

    Dupuis, P., Wang, H.: Optimal stopping with random intervention times. Adv. Appl. Probab. 34, 141–157 (2002)

    MathSciNet  MATH  Article  Google Scholar 

  24. 24.

    Egami, M., Yamazaki, K.: Phase-type fitting of scale functions for spectrally negative Lévy processes. J. Comput. Appl. Math. 264, 1–22 (2014)

    MathSciNet  MATH  Article  Google Scholar 

  25. 25.

    Emery, D.J.: Exit problem for a spectrally positive Lévy process. Adv. Appl. Probab. 5, 498–520 (1973)

    MATH  Article  Google Scholar 

  26. 26.

    François, P., Morellec, E.: Capital structure and asset prices: some effects of bankruptcy procedures. J. Bus. 77, 387–411 (2004)

    Article  Google Scholar 

  27. 27.

    Frank, M.Z., Goyal, V.K.: Trade-off and pecking order theories of debt. In: Eckbo, B.E. (ed.) Handbook of Empirical Corporate Finance, pp. 135–202. Elsevier, Amsterdam (2008)

    Chapter  Google Scholar 

  28. 28.

    Hilberink, B., Rogers, L.C.G.: Optimal capital structure and endogenous default. Finance Stoch. 6, 237–263 (2002)

    MathSciNet  MATH  Article  Google Scholar 

  29. 29.

    Ivanovs, J.: One-Sided Markov Additive Processes and Related Exit Problems. PhD Dissertation, University of Amsterdam (2011). Available online at

  30. 30.

    Ju, N., Parrino, R., Poteshman, A.M., Weisbach, M.S.: Horses and rabbits? Trade-off theory and optimal capital structure. J. Financ. Quant. Anal. 40, 259–281 (2005)

    Article  Google Scholar 

  31. 31.

    Kou, S.G., Wang, H.: First passage times of a jump diffusion process. Adv. Appl. Probab. 35, 504–531 (2003)

    MathSciNet  MATH  Article  Google Scholar 

  32. 32.

    Kraus, A., Litzenberger, R.H.: A state-preference model of optimal financial leverage. J. Finance 28, 911–922 (1973)

    Article  Google Scholar 

  33. 33.

    Kuznetsov, A.: On the convergence of the Gaver–Stehfest algorithm. SIAM J. Numer. Anal. 51, 2984–2998 (2013)

    MathSciNet  MATH  Article  Google Scholar 

  34. 34.

    Kuznetsov, A., Kyprianou, A.E., Pardo, J.C.: Meromorphic Lévy processes and their fluctuation identities. Ann. Appl. Probab. 22, 1101–1135 (2012)

    MathSciNet  MATH  Article  Google Scholar 

  35. 35.

    Kuznetsov, A., Kyprianou, A.E., Rivero, V.: The theory of scale functions for spectrally negative Lévy processes. In: Barndorff-Nielsen, O.E., et al. (eds.) Lévy Matters II. Springer Lecture Notes in Mathematics, vol. 2061, pp. 97–186 (2013)

    MATH  Chapter  Google Scholar 

  36. 36.

    Kyprianou, A.E.: Fluctuations of Lévy Processes with Applications. Springer, Heidelberg (2014)

    MATH  Book  Google Scholar 

  37. 37.

    Kyprianou, A.E., Surya, B.A.: Principles of smooth and continuous fit in the determination of endogenous bankruptcy levels. Finance Stoch. 11, 131–152 (2007)

    MathSciNet  MATH  Article  Google Scholar 

  38. 38.

    Leland, H.E.: Corporate debt value, bond covenants, and optimal capital structure. J. Finance 49, 1213–1252 (1994)

    Article  Google Scholar 

  39. 39.

    Leland, H.E., Toft, K.B.: Optimal capital structure, endogenous bankruptcy, and the term structure of credit spreads. J. Finance 51, 987–1019 (1996)

    Article  Google Scholar 

  40. 40.

    Leung, T., Yamazaki, K., Zhang, H.: An analytic recursive method for optimal multiple stopping: Canadization and phase-type fitting. Int. J. Theor. Appl. Finance 18, 1550032-1–1550032-31 (2015)

    MathSciNet  MATH  Google Scholar 

  41. 41.

    Loeffen, R.L.: An optimal dividends problem with a terminal value for spectrally negative Lévy processes with a completely monotone jump density. J. Appl. Probab. 46, 85–98 (2009)

    MathSciNet  MATH  Article  Google Scholar 

  42. 42.

    Loeffen, R.L., Renaud, J.F., Zhou, X.: Occupation times of intervals until first passage times for spectrally negative Lévy processes with applications. Stoch. Process. Appl. 124, 1408–1435 (2014)

    MATH  Article  Google Scholar 

  43. 43.

    Long, M., Zhang, H.: On the optimality of threshold type strategies in single and recursive optimal stopping under Lévy models. Stoch. Process. Appl. 129, 2821–2849 (2019)

    MATH  Article  Google Scholar 

  44. 44.

    Madan, D.B., Seneta, E.: The variance gamma (VG) model for share market returns. J. Bus. 63, 511–524 (1990)

    Article  Google Scholar 

  45. 45.

    Modigliani, F., Miller, M.: The cost of capital, corporation finance and the theory of investment. Am. Econ. Rev. 48, 267–297 (1958)

    MATH  Google Scholar 

  46. 46.

    Moraux, F.: Valuing corporate liabilities when the default threshold is not an absorbing barrier. EFMA 2002 London Meetings. Available online at

  47. 47.

    Noba, K., Pérez, J.L., Yamazaki, K., Yano, K.: On optimal periodic dividend strategies for Lévy risk processes. Insur. Math. Econ. 80, 29–44 (2018)

    MATH  Article  Google Scholar 

  48. 48.

    Pardo, J.C., Pérez, J.L., Rivero, V.M.: The excursion measure away from zero for spectrally negative Lévy processes. Ann. Inst. Henri Poincaré Probab. Stat. 54, 75–99 (2018)

    MathSciNet  MATH  Article  Google Scholar 

  49. 49.

    Pérez, J.L., Yamazaki, K.: American options under periodic exercise opportunities. Stat. Probab. Lett. 135, 92–101 (2018)

    MathSciNet  MATH  Article  Google Scholar 

  50. 50.

    Pérez, J.L., Yamazaki, K., Bensoussan, A.: Optimal periodic replenishment policies for spectrally positive Lévy processes. Preprint (2018). Available online at

  51. 51.

    Rodosthenous, N., Zhang, H.: Beating the omega clock: an optimal stopping problem with random time-horizon under spectrally negative Lévy models. Ann. Appl. Probab. 28, 2105–2140 (2018)

    MathSciNet  MATH  Article  Google Scholar 

  52. 52.

    Sims, C.A.: Implications of rational inattention. J. Monet. Econ. 50, 665–690 (2003)

    Article  Google Scholar 

  53. 53.

    Surya, B.A.: Optimal Stopping of Lévy Processes and Pasting Principles. PhD dissertation, University of Utrecht (2007). Available online at

  54. 54.

    Surya, B.A., Yamazaki, K.: Optimal capital structure with scale effects under spectrally negative Lévy models. Int. J. Theor. Appl. Finance 17, 1450013-1–1450013-31 (2014)

    MATH  Article  Google Scholar 

  55. 55.

    Takács, L.: Combinatorial Methods in the Theory of Stochastic Processes. Wiley, New York (1966)

    Google Scholar 

  56. 56.

    Zolotarev, V.M.: The first passage time of a level and the behavior at infinity for a class of processes with independent increments. Theory Probab. Appl. 9, 653–664 (1964)

    MATH  Article  Google Scholar 

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The authors thank the anonymous referees and Co-Editor for careful reading of the paper and constructive comments and suggestions. They also thank Nan Chen, Sebastian Gryglewicz, and Tak-Yuen Wong for helpful comments and discussions. This paper was supported by the National Science Centre under the grant 2016/23/B/HS4/00566 (2017-2020) and by MEXT KAKENHI grant no. 17K05377, 19H01791 and 20K03758. Part of the work was completed while Z. Palmowski was visiting Kansai University and Kyoto University at the invitation of K. Yamazaki. Z. Palmowski is very grateful for the hospitality provided by Kazutoshi Yamazaki, Kouji Yano and Takashi Kumagai.

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Appendix A: Relation between the bankruptcy model (1.1) and Parisian ruin

Let \(G\) denote the set of starting points of the negative excursions of the shifted process \((V_{t}-V_{B})_{t \geq 0}\) and consider a set of mutually independent exponential random variables \(\{\mathbf{e}_{\lambda }^{g}:g\in G\}\), independent of \((V_{t})_{t \geq 0}\) as well. Let \(g_{t} :=\sup \{s\leq t:V_{s} \geq V_{B} \}\) be the last time before \(t\) the asset value was at or above \(V_{B}\) (i.e., the starting point of the excursion). Then the Parisian ruin with exponential grace periods is defined as

$$\begin{aligned} \inf \{t >0: V_{t}< V_{B} \text{ and } t>g_{t}+\mathbf{e}_{\lambda }^{g_{t}} \}. \end{aligned}$$

The equivalence with (1.1) can be easily verified. In each negative excursion with starting time \(g\) for the shifted process \((V_{t}-V_{B})_{t\geq 0}\) between two Poisson observation times, say \(T_{i(g)}\) and \(T_{i(g)+1}\) for some \(i(g) \geq 0\), we consider the waiting time \(T_{i(g)+1}-g\) until the next observation. Due to the lack of memory property of the exponential distribution and the strong Markov property, these waiting times are equal in distribution to a set of mutually independent exponentially distributed random variables. Consequently, (1.1) can be written as (A.1) with \(\mathbf{e}_{\lambda }^{g_{t}}\) replaced by these independent exponential random variables. In fact, it has been shown in Baurdoux et al. [10, Remark 1.1] that the joint distribution of the bankruptcy time (1.1) and the corresponding position of \(X\) is the same as that of (A.1) and the corresponding position of \(X\) (refer to Avram et al. [9] and Pardo et al. [48] for related literature).

It is worth investigating which impact the randomness of the grace period has on the asset values at bankruptcy. To this end, we compare in Table 2 the expected discounted asset values at bankruptcy for the cases when the grace periods are constant or exponentially distributed (with the common mean \(\lambda ^{-1}\)). When \(\lambda \) is low, the random (exponential) case tends to overestimate the asset value, but as \(\lambda \) becomes larger (i.e., observation is more frequent), the differences become smaller. This implies that when the observation is frequent, our model can approximate the constant grace period case reasonably well.

Table 2 The discounted asset values at bankruptcy \(\mathbb{E}[e^{-r \tau _{V_{B}}^{-}}V_{\tau _{V_{B}}^{-}} \mathbf{1}_{ \{\tau _{V_{B}}^{-} < \infty \}} ]\) when \(\tau _{V_{B}}^{-}\) is the bankruptcy time with constant or exponential grace periods with mean \(\lambda ^{-1}\). The approximated values via Monte Carlo simulation are displayed together with their 95% confidence intervals. We set \(r = 7.5 \%\) and use the Lévy processes given in Cases A (without jumps) and B (with negative jumps) specified in Sect. 6 so that \((e^{-(r-\delta ) t} V_{t})_{t \geq 0}\) is a martingale for \(\delta = 7 \%\). The initial value of the process is 100 and the bankruptcy level \(V_{B}\) is 40

Appendix B: Proof of Proposition 3.2

For brevity, throughout this appendix, we use the notation

$$\begin{aligned} z_{T} := z - \log V_{T}, \qquad z \in \mathbb{R}. \end{aligned}$$

We first obtain the \(q\)-resolvent measure of the spectrally negative Lévy process \((X_{t})_{t \geq 0}\) killed at the stopping time (3.6) in terms of the function \(H^{(q+\lambda )}(\, \cdot \, ; \theta )\) as in (3.5) and

$$\begin{aligned} I^{(q, \lambda )}(x,y) &:= W^{(q+\lambda )}(x+y)-\lambda \int _{0}^{x}W^{(q)}(x-z)W^{(q+ \lambda )}(z+y) \mathrm{d}z \\ &\phantom{=::}-Z^{(q)}\big(x;\Phi (q+\lambda )\big)W^{(q+\lambda )}(y), \qquad q > 0, x, y \in \mathbb{R}. \end{aligned}$$

The proof of the following result is given in Appendix D.

Theorem B.1

For any bounded measurable function \(h:\mathbb{R}\to \mathbb{R}\)with compact support,

$$\begin{aligned} \mathbb{E}_{x}\bigg[ \int _{0}^{\tilde{T}_{z}^{-} } e^{-qt} h(X_{t}) { \mathrm{d}}t \bigg]= \int _{\mathbb{R}} h(y+z)R^{(q,\lambda )}(x-z,y) { \mathrm{d}}y, \qquad x, z \in \mathbb{R}, \end{aligned}$$


$$\begin{aligned} R^{(q,\lambda )}(x,y)&:=Z^{(q)}\big(x;\Phi (q+\lambda )\big) \frac{\Phi (q+\lambda )- \Phi (q)}{\lambda } H^{(q+\lambda )}\big(-y; \Phi (q)\big) \\ &\phantom{=::}- I^{(q, \lambda )}(x,-y). \end{aligned}$$

Using Theorem B.1, we show Proposition 3.2. The case \(V_{T} = 0\) is trivial, and hence we assume \(V_{T} > 0\) for the rest of this proof. By integrating the density in Theorem B.1 and using (B.1), we can write (3.9) as

$$\begin{aligned} \Lambda ^{(r,\lambda )}(x,z)&= Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \frac{\Phi (r+\lambda )- \Phi (r)}{\lambda } \mathcal{H}(z) - \mathcal{I}(x,z), \end{aligned}$$

where we define

$$\begin{aligned} \mathcal{H}(z) := \int _{-\infty }^{z_{T}} H^{(r+\lambda )}\big(y; \Phi (r)\big)\mathrm{d}y, \qquad \mathcal{I}(x,z) := \int _{-\infty }^{z_{T}} I^{(r, \lambda )}(x-z,y)\mathrm{d}y, \end{aligned}$$

which are shown to be finite immediately below. The rest of the proof of Proposition 3.2 is devoted to the simplification of the integrals ℋ and ℐ.

Lemma B.2

We have \(\overline{W}^{(r+\lambda )}(y) -\lambda \int _{0}^{y}W^{(r)}(y-z) \overline{W}^{(r+\lambda )}(z) \mathrm{d}z= \overline{W}^{(r)}(y)\)for all \(y \in \mathbb{R}\).


We have

$$\begin{aligned} &\frac{\partial }{\partial y} \bigg(\overline{W}^{(r+\lambda )}(y) - \lambda \int _{0}^{y}W^{(r)}(y-z) \overline{W}^{(r+\lambda )}(z) { \mathrm{d}}z \bigg) \\ & = \frac{\partial }{\partial y} \bigg(\overline{W}^{(r+\lambda )}(y) - \lambda \int _{0}^{y}W^{(r)}(z) \overline{W}^{(r+\lambda )}(y-z) { \mathrm{d}}z \bigg) \\ & =W^{(r+\lambda )}(y) -\lambda \int _{0}^{y}W^{(r)}(z) W^{(r+ \lambda )}(y-z) \mathrm{d}z = W^{(r)}(y), \end{aligned}$$

where the last equality holds by Loeffen et al. [42, identity (6)]. Integrating this and because \(\overline{W}^{(r+\lambda )}(0) = \overline{W}^{(r)}(0) = 0\), the proof is complete. □

Lemma B.3

We have for \(x,z \in \mathbb{R}\) that

$$\begin{aligned} \mathcal{I}(x,z)&=\overline{W}^{(r+\lambda )}(x- \log V_{T}) \mathbf{1}_{\{z_{T}>0\}} + \overline{W}^{(r)}(x-\log V_{T}) \mathbf{1}_{\{z_{T}\leq 0\}} \\ &\phantom{=:}-\lambda \int _{0}^{x-z}W^{(r)}(x-z-u) \overline{W}^{(r+\lambda )}(u+z_{T}) \mathrm{d}u \mathbf{1}_{\{z_{T}>0\}} \\ &\phantom{=:}-Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \overline{W}^{(r+\lambda )}(z_{T}). \end{aligned}$$


For \(z_{T}> 0\), we have

$$\begin{aligned} &\int _{0}^{z_{T}} I^{(r, \lambda )}(x-z,y)\mathrm{d}y \\ &=\int _{0}^{z_{T}}\!W^{(r+\lambda )}(x-z+y) \mathrm{d}y -\lambda \int _{0}^{x-z}W^{(r)}(x-z-u) \int _{0}^{z_{T}}\! W^{(r+\lambda )}(u+y) \mathrm{d}y \mathrm{d}u \\ &\phantom{=:} -Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \int _{0}^{z_{T}} W^{(r+ \lambda )}(y) \mathrm{d}y \\ &=\overline{W}^{(r+\lambda )}(x- \log V_{T})-\overline{W}^{(r+ \lambda )}(x-z) \\ &\phantom{=:}- \lambda \int _{0}^{x-z}W^{(r)}(x-z-u) \big(\overline{W}^{(r+ \lambda )}(u+z_{T} )-\overline{W}^{(r+\lambda )}(u) \big) \mathrm{d}u \\ &\phantom{=:} -Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \overline{W}^{(r+\lambda )}(z_{T} ) \\ &=\overline{W}^{(r+\lambda )}(x- \log V_{T})-\overline{W}^{(r)}(x-z) \\ &\phantom{=:}-\lambda \int _{0}^{x-z}W^{(r)}(x-z-u) \overline{W}^{(r+\lambda )}(u+z_{T}) \mathrm{d}u \\ &\phantom{=:}-Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \overline{W}^{(r+\lambda )}(z_{T}), \end{aligned}$$

where we used \(x-z+z_{T} = x - \log V_{T}\) (see (B.1)) in the second equality and Lemma B.2 in the last one. On the other hand, as in Pérez et al. [50, Remark 4.3(ii)], we have

$$\begin{aligned} I^{(r, \lambda )}(x,y)=W^{(r)}(x+y), \qquad y < 0, \end{aligned}$$

and therefore

$$\begin{aligned} \int _{-\infty }^{0\wedge z_{T}} I^{(r, \lambda )}(x-z,y)\mathrm{d}y= \int _{-\infty }^{0\wedge z_{T}} W^{(r)}(x-z+y)\mathrm{d}y=\overline{W}^{(r)} \big(x-z+(0\wedge z_{T})\big). \end{aligned}$$

Now the result is immediate by adding the two integrals and using (again see (B.1))

$$\begin{aligned} \overline{W}^{(r)}\big(x-z+(0\wedge z_{T})\big) = \left \{ \textstyle\begin{array}{ll} \overline{W}^{(r)}(x-z) &\quad \textrm{if } z_{T} > 0, \\ \overline{W}^{(r)}(x-\log V_{T}) & \quad \textrm{if } z_{T} \leq 0. \end{array}\displaystyle \right . \end{aligned}$$


We note that (B.3) together with Lemma B.3 implies that

$$ \Lambda ^{(r,\lambda )}(z,z)= \frac{\Phi (r+\lambda )- \Phi (r)}{\lambda } \int _{-\infty }^{z_{T}} H^{(r+ \lambda )}\big(y; \Phi (r)\big)\mathrm{d}y, \qquad z \in \mathbb{R}. $$

Lemma B.4

For \(z \in \mathbb{R}\), we have

$$\begin{aligned} \mathcal{H}(z) = \frac{1}{\Phi (r)} \bigg(Z^{(r+\lambda )}\big(z_{T}; \Phi (r)\big)-\lambda \frac{\Phi (r+\lambda )}{\Phi (r+\lambda )- \Phi (r)}\overline{W}^{(r+ \lambda )}(z_{T}) \bigg). \end{aligned}$$


First, by (3.5), we have

$$\begin{aligned} H^{(r+\lambda )}\big(y;\Phi (r)\big) &= e^{\Phi (r)y}\bigg(1+\lambda \int _{0}^{y}e^{-\Phi (r)u}W^{(r+\lambda )}(u)\mathrm{d}u\bigg) \\ &\phantom{=:}-\frac{\lambda }{\Phi (r+\lambda )-\Phi (r)}W^{(r+\lambda )}(y), \qquad y \in \mathbb{R}, \end{aligned}$$

where in particular \(H^{(r+\lambda )}(y;\Phi (r)) = e^{\Phi (r)y}\) for \(y < 0\). For \(z_{T}>0\),

$$\begin{aligned} &\int ^{z_{T}}_{0} e^{\Phi (r)y}\int _{0}^{y} e^{-\Phi (r)u}W^{(r+ \lambda )}(u)\mathrm{d}u\mathrm{d}y \\ &= \int ^{z_{T}}_{0} \int _{u}^{z_{T}} e^{\Phi (r)y}e^{-\Phi (r)u}W^{(r+ \lambda )}(u)\mathrm{d}y \mathrm{d}u \\ &= \int ^{z_{T}}_{0} \frac{e^{\Phi (r) z_{T}} - e^{\Phi (r) u}}{\Phi (r)} e^{-\Phi (r)u}W^{(r+ \lambda )}(u) \mathrm{d}u \\ &= \frac{1}{\Phi (r)} \bigg( \int ^{z_{T}}_{0} e^{\Phi (r) (z_{T}-u)} W^{(r+ \lambda )}(u) \mathrm{d}u - \overline{W}^{(r+\lambda )}(z_{T}) \bigg), \end{aligned}$$

and hence

$$\begin{aligned} \begin{aligned} &\int ^{z_{T}}_{0}H^{(r+\lambda )}\big(y;\Phi (r)\big)\mathrm{d}y \\ &=\int ^{z_{T}}_{0} \bigg( e^{\Phi (r)y}\Big(1+\lambda \int _{0}^{y}e^{- \Phi (r)u}W^{(r+\lambda )}(u)\mathrm{d}u\Big) \\ &\phantom{=:}\qquad \qquad -\frac{\lambda }{\Phi (r+\lambda )-\Phi (r)}W^{(r+ \lambda )}(y) \bigg) \mathrm{d}y \\ &=\frac{1}{\Phi (r)} \bigg( e^{\Phi (r)z_{T}}-1+\lambda \int _{0}^{z_{T}}e^{ \Phi (r)(z_{T}-u)}W^{(r+\lambda )}(u)\mathrm{d}u \\ &\phantom{=:}\qquad \qquad -\lambda \frac{\Phi (r+\lambda )}{\Phi (r+\lambda )- \Phi (r)}\overline{W}^{(r+ \lambda )}(z_{T}) \bigg) \\ &=\frac{1}{\Phi (r)} \bigg( Z^{(r+\lambda )}\big(z_{T};\Phi (r)\big)-1- \lambda \frac{\Phi (r+\lambda )}{\Phi (r+\lambda )- \Phi (r)} \overline{W}^{(r+\lambda )}(z_{T}) \bigg). \end{aligned} \end{aligned}$$

On the other hand, for \(z_{T}\in \mathbb{R}\),

$$ \int ^{z_{T} \wedge 0}_{-\infty } H^{(r+\lambda )}\big(y; \Phi (r) \big)\mathrm{d}y = \int ^{z_{T} \wedge 0}_{-\infty } e^{\Phi (r)y}{\mathrm{d}}y = e^{\Phi (r)(z_{T} \wedge 0) } / \Phi (r). $$

By adding up the integrals, we obtain (B.7). □

Now applying Lemmas B.3 and B.4 in (B.3), we get Proposition 3.2. □

Appendix C: Other proofs

C.1 Proof of Lemma 4.1

For the case \(V_{T} > 0\),

$$ \Lambda ^{(r,\lambda )}(z,z)=\mathbb{E}_{z} \bigg[ \int _{0}^{ \tilde{T}^{-}_{z}} e^{-rt}\mathbf{1}_{\{X_{t}\geq \log V_{T}\}} {\mathrm{d}}t \bigg]=\mathbb{E}_{0} \bigg[ \int _{0}^{\tilde{T}^{-}_{0}} e^{-rt} \mathbf{1}_{\{X_{t}\geq \log V_{T}-z\}} {\mathrm{d}}t \bigg] $$

is clearly nondecreasing in \(z\), and by bounded convergence, \(\lim _{z \downarrow -\infty }\Lambda ^{(r,\lambda )}(z,z) =0\).

On the other hand, if \(V_{T}=0\), then Proposition 3.2 and Remark 3.1, 1) yield \(\Lambda ^{(r,\lambda )}(z,z) =\frac{1}{r}(1-J^{(r, \lambda )}(0;0))= \frac{1}{\lambda +r} \frac{\Phi (r+\lambda )}{\Phi (r)}\).  □

C.2 Proof of Proposition 4.5

We start from several key introductory identities. Fix \(q > 0\). Because

$$\begin{aligned} e^{\theta z}Z^{({q})}(x-z;\theta ) &= e^{\theta x} \bigg( 1 + \big({q}- \psi (\theta )\big) \int _{0}^{x-z} e^{-\theta u} W^{({q})}(u) \mathrm{d}u \bigg), \end{aligned}$$

we have for \(x \neq z\) that

$$\begin{aligned} \frac{\partial }{\partial z} \big(e^{\theta z}Z^{({q})}(x-z;\theta ) \big) &= - e^{\theta z} \big({q}- \psi (\theta )\big) W^{({q})}(x-z), \\ \frac{\partial }{\partial x}Z^{(q)}(x-z;\theta ) &= \frac{\partial }{\partial x} \bigg( e^{\theta (x-z)} \Big( 1 + \big(q- \psi (\theta )\big) \int _{0}^{x-z} e^{-\theta u} W^{(q)}(u) \mathrm{d}u \Big) \bigg) \\ &= \theta Z^{(q)}(x-z;\theta ) + \big(q- \psi (\theta )\big) W^{(q)}(x-z). \end{aligned}$$

In particular,

$$\begin{aligned} \frac{\partial }{\partial x}Z^{(q)}\big(x-z;\Phi (r+\lambda )\big) &= \Phi (r+\lambda ) Z^{(q)}\big(x-z;\Phi (r+\lambda )\big) -\lambda W^{(q)}(x-z). \end{aligned}$$

Moreover, we have for \(x \neq z\) that

$$\begin{aligned} &\frac{\partial }{\partial x} J^{(q, \lambda )}(x-z; \theta ) \\ &=\frac{\lambda }{\lambda +{q}-\psi (\theta )} \frac{\partial }{\partial x} Z^{({q})}(x-z;\theta ) \\ &\phantom{=:} - \frac{\psi (\theta )-{q}}{\lambda +{q}-\psi (\theta )} \frac{\Phi ({q}+\lambda )-\Phi ({q})}{\theta -\Phi ({q})} \frac{\partial }{\partial x} Z^{({q})}\big(x-z;\Phi ({q}+\lambda ) \big) \\ &= \frac{\lambda }{\lambda +{q}-\psi (\theta )} \theta Z^{({q})}(x-z; \theta ) \\ &\phantom{=:}- \frac{\psi (\theta )-{q}}{\lambda +{q}-\psi (\theta )} \frac{\Phi ({q}+\lambda )-\Phi ({q})}{\theta -\Phi ({q})} \Phi (q+ \lambda ) Z^{({q})}\big(x-z;\Phi (q+\lambda )\big) \\ &\phantom{=:} + \frac{\psi (\theta )-{q}}{\lambda +{q}-\psi (\theta )} \frac{\Phi ({q}+\lambda )-\theta }{\theta -\Phi ({q})} \lambda W^{({q})}(x-z). \end{aligned}$$

By setting \(\theta = 0\), we obtain the following result.

Lemma C.1

We have for \(x \neq z\) and \(q > 0\) that

$$\begin{aligned} \frac{\partial }{\partial z} J^{(q, \lambda )}(x-z; 0)&=- \frac{\partial }{\partial x} J^{(q, \lambda )}(x-z; 0) \\ &=\frac{{q}}{\lambda +{q}} \frac{\Phi ({q}+\lambda )-\Phi ({q})}{\Phi ({q})} \Phi (q+\lambda )H^{(q)} \big(x-z; \Phi (q+\lambda )\big). \end{aligned}$$

Noting that \(\frac{\partial }{\partial z} ( e^{z} J^{(q, \lambda )}(x-z;1) ) = e^{z} J^{(q, \lambda )}(x-z;1) - e^{z} \frac{\partial }{\partial x} J^{(q, \lambda )}(x-z;1)\) and using (C.2) with \(\theta =1\), we have the following result.

Lemma C.2

We have for \(x \neq z\) and \(q > 0\) that

$$\begin{aligned} &\frac{\partial }{\partial z} \big( e^{z} J^{(q, \lambda )}(x-z;1) \big) \\ &\quad =\frac{\psi (1)-{q}}{\lambda +{q}-\psi (1)} \frac{\Phi ({q}+\lambda )-\Phi ({q})}{1-\Phi ({q})} \big(\Phi (q+ \lambda ) -1 \big) e^{z} H^{(q)}\big(x-z; \Phi (q+\lambda )\big). \end{aligned}$$

We also need the following observation.

Lemma C.3

We have for \(z_{T}\neq0\) and \(x > z\) that

$$\begin{aligned} &\frac{\partial }{\partial z} \Lambda ^{(r,\lambda )}(x,z) =- \frac{(\Phi (r+\lambda )- \Phi (r))^{2}}{\lambda }H^{(r)}\big(x-z; \Phi (r+\lambda )\big) \mathcal{H}(z). \end{aligned}$$


By differentiating the identity in Lemma B.3, for \(z_{T}\neq0\), by (C.1),

$$\begin{aligned} \frac{\partial }{\partial z} \mathcal{I}(x,z)& = -\lambda \frac{\partial }{\partial z}\int _{0}^{x-z}W^{(r)}(w) \overline{W}^{(r+ \lambda )}(x-w- \log V_{T}) \mathrm{d}w \mathbf{1}_{\{ z_{T}>0\}} \\ &\phantom{=:}+\frac{\partial }{\partial x}Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \overline{W}^{(r+\lambda )}(z_{T} ) \\ &\phantom{=:} -Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \frac{\partial }{\partial z} \overline{W}^{(r+\lambda )}(z_{T} ) \\ &= \lambda W^{(r)}(x-z) \overline{W}^{(r+\lambda )}(z_{T}) \\ &\phantom{=:}+\Big(\Phi (r+\lambda ) Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) - \lambda W^{(r)}(x-z) \Big) \overline{W}^{(r+\lambda )}(z_{T} ) \\ &\phantom{=:}-Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) W^{(r+\lambda )}(z_{T} ) \\ &=Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \big( \Phi (r+\lambda ) \overline{W}^{(r+\lambda )}(z_{T} ) - W^{(r+\lambda )}(z_{T} ) \big). \end{aligned}$$

By (3.5) and (C.1), we can write

$$\begin{aligned} \frac{\partial }{\partial x}Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) &= \big(\Phi ({r}+\lambda )-\Phi ({r})\big) H^{(r)}\big(x-z; \Phi (r+ \lambda )\big) \\ &\phantom{=:}+\Phi ({r}) Z^{({r})}\big(x-z;\Phi (r+\lambda )\big). \end{aligned}$$

Using (B.4), we have for \(x > z\) and \(z_{T}\neq0\) that

$$\begin{aligned} \frac{\partial }{\partial z}\Big(Z^{(r)}\big(x-z;\Phi (r+\lambda ) \big) \mathcal{H}(z) \Big) &=- \frac{\partial }{\partial x}Z^{(r)} \big(x-z;\Phi (r+\lambda )\big) \mathcal{H}(z) \\ &\phantom{=:}+Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) H^{(r+\lambda )}\big(z_{T}; \Phi (r)\big). \end{aligned}$$

By (B.7) and (C.4), this equals

$$\begin{aligned} &- \big(\Phi (r+\lambda )- \Phi (r)\big) H^{(r)}\big(x-z;\Phi (r+ \lambda )\big) \mathcal{H}(z) \\ & +Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \Big( H^{(r+\lambda )}\big(z_{T}; \Phi (r)\big) - \Phi (r) \mathcal{H}(z) \Big). \end{aligned}$$

Furthermore, by (B.7),

$$\begin{aligned} &H^{(r+\lambda )}\big(z_{T};\Phi (r)\big) - \Phi (r) \mathcal{H}(z) \\ &= H^{(r+\lambda )}\big(z_{T};\Phi (r)\big) -Z^{(r+\lambda )}\big(z_{T}; \Phi (r)\big)+\lambda \frac{\Phi (r+\lambda )}{\Phi (r+\lambda )- \Phi (r)}\overline{W}^{(r+ \lambda )}(z_{T}) \\ &=\frac{\lambda }{\Phi (r+\lambda )-\Phi (r)} \big(\Phi (r+\lambda ) \overline{W}^{(r+\lambda )}(z_{T}) - W^{(r+\lambda )}(z_{T}) \big). \end{aligned}$$

In sum, we have

$$\begin{aligned} &\frac{\partial }{\partial z}\Big(Z^{(r)}\big(x-z;\Phi (r+\lambda ) \big) \mathcal{H}(z) \Big) \\ &=- {\big(\Phi (r+\lambda )- \Phi (r)\big)} H^{(r)}\big(x-z;\Phi (r+ \lambda )\big) \mathcal{H}(z) \\ &\phantom{=:}+ \frac{\lambda }{\Phi (r+\lambda )-\Phi (r)} Z^{(r)}\big(x-z;\Phi (r+ \lambda )\big) \\ &\phantom{=:+}\times \big(\Phi (r+\lambda ) \overline{W}^{(r+\lambda )}(z_{T}) - W^{(r+ \lambda )}(z_{T}) \big). \end{aligned}$$

By applying (C.3) and (C.6) in (B.3), the proof is complete. □

We now prove Proposition 4.5. Differentiating (3.11) and using Lemmas C.1C.3 gives

$$\begin{aligned} &\frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}) \\ &=- V_{B}^{-1}\bigg( \alpha \frac{\psi (1)-r}{\lambda +{r}-\psi (1)} \frac{\Phi (r+\lambda )-\Phi (r)}{1-\Phi (r)} \big(\Phi (r+\lambda ) -1 \big) V_{B} \\ &\phantom{=:}\qquad \qquad +P \kappa \rho \frac{(\Phi (r+\lambda )- \Phi (r))^{2}}{\lambda } \int _{-\infty }^{ \log (V_{B}/V_{T})} H^{(r+\lambda )}\big(y; \Phi (r)\big)\mathrm{d}y \bigg) \\ &\phantom{=:+}\times H^{(r)} \bigg(\log \frac{V}{V_{B}}; \Phi (r+\lambda ) \bigg) \\ &\phantom{=:}- V_{B}^{-1}\bigg( (1-\alpha ) \frac{\psi (1)-{r -m}}{\lambda +r+m-\psi (1)} \frac{\Phi (r+m+\lambda )-\Phi (r+m)}{1-\Phi (r+m)} \\ &\phantom{=}\qquad \qquad \quad \times \big(\Phi (r+m+\lambda ) -1\big) V_{B} \\ &\phantom{=}\qquad \qquad \quad - \frac{P \rho + p}{r+m} \frac{r+m}{\lambda +{r+m}} \frac{\Phi (r+m+\lambda )-\Phi (r+m)}{\Phi (r+m)}\Phi (r+m+\lambda ) \bigg) \\ & \phantom{=:+}\times H^{(r+m)}\bigg(\log \frac{V}{V_{B}}; \Phi (r+m+\lambda ) \bigg), \end{aligned}$$

which reduces to (4.5) after simplification using Remark 3.1, 1). □

C.3 Proof of Proposition 4.6

In view of the probabilistic expression (3.5), \(q \mapsto H^{(q)}(x-z; \Phi (q+\lambda ))\) is nonincreasing for \(x,z\in \mathbb{R}\), and hence

$$\begin{aligned} \frac{H^{(r)}(x-z; \Phi (r+\lambda ))}{H^{(r+m)}(x-z; \Phi (r+m+\lambda ))} \geq 1 \qquad \text{for $x,z\in \mathbb{R}$}. \end{aligned}$$

On the other hand, because \(\psi \) is strictly convex and strictly increasing on \([\Phi (0), \infty )\), its right inverse \(\Phi \) is strictly concave, that is, \(\Phi '(r+\lambda +x)-\Phi '(r+x)<0\) for \(x, \lambda > 0\). Therefore

$$\begin{aligned} \frac{\Phi (r+\lambda )-\Phi (r)}{\Phi (r+m+\lambda )-\Phi (r+m)} > 1 \qquad \text{for $\lambda >0$}. \end{aligned}$$

Combining these, we obtain

$$\begin{aligned} \frac{\Phi (r+\lambda )-\Phi (r)}{\Phi (r+m+\lambda )-\Phi (r+m)} \frac{H^{(r)}(x-z; \Phi (r+\lambda ))}{H^{(r+m)}(x-z; \Phi (r+m+\lambda ))}> 1. \end{aligned}$$

By Remark 3.1, 2) and because (3.5) implies that \(H^{(r+\lambda )}\) is nonnegative on ℝ, we have

$$\begin{aligned} \alpha \big(1-J^{(r, \lambda )}(0;1)\big)e^{z}+P \kappa \rho \frac{\Phi (r+\lambda )- \Phi (r)}{\lambda } \mathcal{H}(z) \geq 0. \end{aligned}$$

Combining this with (B.6), (C.7) and (4.2) gives

$$\begin{aligned} &L(\log V, \log V_{B}) \\ &= \frac{H^{(r)}(\log V-\log V_{B}; \Phi (r+\lambda ))}{H^{(r+m)}(\log V-\log V_{B}; \Phi (r+m+\lambda ))} \frac{\Phi (r+\lambda )-\Phi (r)}{\Phi (r+m+\lambda )-\Phi (r+m)} \\ &\phantom{=:}\times \bigg(\alpha \big(1-J^{(r, \lambda )}(0;1)\big) V_{B} \\ &\phantom{=:}\qquad +P \kappa \rho \frac{\Phi (r+\lambda )- \Phi (r)}{\lambda } \int _{-\infty }^{\log V_{B}- \log V_{T}} H^{(r+\lambda )}\big(y; \Phi (r)\big)\mathrm{d}y \bigg) \\ &\phantom{=:}+(1-\alpha )\big(1-J^{(r+m, \lambda )}(0;1)\big) V_{B}- \frac{P \rho + p}{r+m}\big(1-J^{(r+m, \lambda )}(0;0)\big) \\ &> \alpha \big(1-J^{(r, \lambda )}(0;1)\big) V_{B}+P \kappa \rho \Lambda ^{(r,\lambda )} (\log V_{B}, \log V_{B}) \\ &\phantom{=:}+(1-\alpha )\big(1-J^{(r+m, \lambda )}(0;1)\big) V_{B}- \frac{P \rho + p}{r+m}\big(1-J^{(r+m, \lambda )}(0;0)\big) \\ &= \mathcal{E}(V_{B}; V_{B}). \end{aligned}$$

In addition, because \(V_{B} \geq V_{B}^{*}\), the monotonicity in Proposition 4.2 implies that \(\mathcal{E}(V_{B};V_{B}) \geq 0\). Note when \(V_{B}^{*} = 0\) that \(\mathcal{E}(V_{B};V_{B}) \geq 0\) for all \(V_{B} > 0\) by Proposition 4.2.

Now by Proposition 4.5 and recalling that \(H^{(r+m)}\) is positive,

$$\begin{aligned} &\frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}) \\ &< - \big(\Phi (r+m+\lambda )-\Phi (r+m)\big)H^{(r+m)}\bigg(\log \frac{V}{V_{B}}; \Phi (r+m+\lambda ) \bigg) \frac{\mathcal{E}(V_{B};V_{B})}{V_{B}} \\ & \leq 0. \end{aligned}$$


C.4 Proof of Proposition 4.7

Using Lemma B.3 together with (C.1) and (C.3), for \(x\neq\log V_{T}\) and \(z \in \mathbb{R}\) such that \(z_{T} \neq 0\), we have

$$\begin{aligned} \frac{\partial }{\partial x} \mathcal{I}(x,z) &=W^{(r+\lambda )}(x- \log V_{T}) \mathbf{1}_{\{ z_{T}>0\}} + W^{(r)}(x-\log V_{T}) \mathbf{1}_{\{ z_{T} < 0\}} \\ &\phantom{=:}- \frac{\partial }{\partial x}\lambda \int _{0}^{x-z}W^{(r)}(w) \overline{W}^{(r+\lambda )}(x-z-w+z_{T}) \mathrm{d}w \mathbf{1}_{\{ z_{T}>0 \}} \\ &\phantom{=:}-\frac{\partial }{\partial x}Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) \overline{W}^{(r+\lambda )}(z_{T}) \\ &=W^{(r+\lambda )}(x- \log V_{T}) \mathbf{1}_{\{ z_{T}>0\}} + W^{(r)}(x- \log V_{T}) \mathbf{1}_{\{ z_{T} < 0\}} \\ &\phantom{=:}- \lambda \int _{0}^{x-z}W^{(r)}(w) W^{(r+\lambda )}(x-z-w+z_{T}) { \mathrm{d}}w \mathbf{1}_{\{ z_{T}>0\}} \\ &\phantom{=:} -\lambda W^{(r)}(x-z) \overline{W}^{(r+\lambda )}(z_{T}) \\ &\phantom{=:}- \Big(\Phi (r+\lambda ) Z^{(r)}\big(x-z;\Phi (r+\lambda )\big) - \lambda W^{(r)}(x-z) \Big) \overline{W}^{(r+\lambda )}(z_{T}) \\ &=I^{(r, \lambda )}(x-z,z_{T})-\frac{\partial }{\partial z} \mathcal{I}(x,z), \end{aligned}$$

where we used (B.5) for the case \(z_{T} <0\). Hence using (C.5) and (C.8) in (B.3), and by (B.2),

$$\begin{aligned} \frac{\partial }{\partial x}\Lambda ^{(r,\lambda )}(x,z)&=- \frac{\partial }{\partial z}\Lambda ^{(r,\lambda )}(x,z)+R^{(r, \lambda )}(x-z,-z_{T}). \end{aligned}$$

Now we write (3.11) as

$$\begin{aligned} \mathcal{E}(V;V_{B}) &=\mathcal{A}(\log V, \log V_{B})+P \kappa \rho \Lambda ^{(r,\lambda )}(\log V, \log V_{B}), \end{aligned}$$


$$\begin{aligned} \mathcal{A}(x,z) &:= e^{x} -\alpha e^{z} J^{(r, \lambda )}(x-z; 1) - \frac{P \rho + p}{r+m} \big(1- J^{(r+m, \lambda )}(x-z;0) \big) \\ &\phantom{=::}- \left (1-\alpha \right ) e^{z} J^{(r+m, \lambda )}(x-z; 1). \end{aligned}$$

Differentiating this with respect to \(x\) and \(z\), we get

$$\begin{aligned} \frac{\partial }{\partial x}\mathcal{A}(x,z) &= e^{x} - \alpha e^{z} \frac{\partial }{\partial x} J^{(r, \lambda )}(x-z; 1) + \frac{P \rho + p}{r+m} \frac{\partial }{\partial x} J^{(r+m, \lambda )}(x-z;0) \\ &\phantom{=:}- \left (1-\alpha \right ) e^{z} \frac{\partial }{\partial x} J^{(r+m, \lambda )}(x-z; 1), \\ \frac{\partial }{\partial z}\mathcal{A}(x,z) &= - \alpha e^{z} J^{(r, \lambda )}(x-z; 1) + \alpha e^{z} \frac{\partial }{\partial x} J^{(r, \lambda )}(x-z; 1) \\ &\phantom{=:}- \frac{P \rho + p}{r+m} \frac{\partial }{\partial x} J^{(r+m, \lambda )}(x-z;0) - \left (1-\alpha \right ) e^{z} J^{(r+m, \lambda )}(x-z; 1) \\ &\phantom{=:}+ \left (1-\alpha \right ) e^{z} \frac{\partial }{\partial x} J^{(r+m, \lambda )}(x-z; 1), \end{aligned}$$

and hence

$$\begin{aligned} \frac{\partial }{\partial x} \mathcal{A}(x,z)&=e^{x}- \frac{\partial }{\partial z} \mathcal{A}(x,z)-\alpha e^{z} J^{(r, \lambda )}(x-z;1) \\ &\phantom{=:}-(1-\alpha )e^{z} J^{(r+m, \lambda )}(x-z;1). \end{aligned}$$

Finally, using (C.9) and (C.11) in (C.10), we obtain

$$\begin{aligned} \frac{\partial }{\partial V} \mathcal{E}(V;V_{B}) &= \frac{1}{V} \frac{\partial }{\partial x}\big( \mathcal{A}(x, \log V_{B})+P \kappa \rho \Lambda ^{(r,\lambda )}(x, \log V_{B}) \big) \bigg|_{x=\log V} \\ &= \frac{1}{V} \bigg( V -\frac{\partial }{\partial z} \mathcal{A}(\log V,z) \bigg|_{z = \log V_{B}}-\alpha V_{B} J^{(r, \lambda )} \Big(\log \frac{V}{V_{B}};1 \Big) \\ &\phantom{=:}\qquad -(1-\alpha )V_{B} J^{(r+m, \lambda )}\Big(\log \frac{V}{V_{B}};1 \Big) \\ &\phantom{=:}\qquad -P \kappa \rho \frac{\partial }{\partial z} \Lambda ^{(r, \lambda )}(\log V,z) \bigg|_{z = \log V_{B}} \\ &\phantom{=:}\qquad + P \kappa \rho R^{(r,\lambda )} \Big(\log \frac{V}{V_{B}}, \log \frac{V_{T}}{V_{B}} \Big)\bigg), \end{aligned}$$

which reduces to the desired expression by noting that (C.10) gives

$$\begin{aligned} \frac{\partial }{\partial V_{B}} \mathcal{E}(V;V_{B}) = \frac{1}{V_{B}} \bigg( \frac{\partial }{\partial z} \mathcal{A}(\log V,z) \bigg|_{z = \log V_{B}}+ P \kappa \rho \frac{\partial }{\partial z} \Lambda ^{(r,\lambda )}(\log V,z) \bigg|_{z = \log V_{B}} \bigg). \end{aligned}$$


C.5 Proof of Lemma 4.10

First we note by Bertoin [11, Theorem VII.4] that for \(q\geq 0\),

$$\begin{aligned} \lim _{\lambda \to \infty } \frac{\Phi (\lambda +r+m)}{\Phi (\lambda +q)}=1. \end{aligned}$$

On the other hand, (B.6) implies for \(V_{B}> 0\) that

$$\begin{aligned} &\frac{\lambda }{\Phi (r+\lambda )-\Phi (r)}\Lambda ^{(r,\lambda )}( \log V_{B},\log V_{B}) \\ &= \textstyle\begin{cases} \frac{1}{\Phi (r)} (\frac{V_{B}}{V_{T}} )^{\Phi (r)} &\quad \textrm{if } V_{B}/V_{T} < 1, \\ \frac{1}{\Phi (r)} +\int _{0}^{\log (V_{B}/V_{T})} H^{(r+\lambda )}(y; \Phi (r))\mathrm{d}y &\quad \textrm{if } V_{B}/V_{T} \geq 1, \end{cases}\displaystyle \end{aligned}$$

where we used \(H^{(r+\lambda )}(y;\Phi (r)) = \exp (\Phi (r)y)\) for \(y \leq 0\). In addition, by the probabilistic expression of \(H^{(r+\lambda )}\) given in (3.5) and using dominated convergence, we have

$$\begin{aligned} \lim _{\lambda \to \infty } \int _{0}^{\log (V_{B}/V_{T})} H^{(r+ \lambda )}\big(y;\Phi (r)\big)\mathrm{d}y=0. \end{aligned}$$

This together with (C.12) gives

$$\begin{aligned} \lim _{\lambda \to \infty }\frac{\lambda +r+m }{\Phi (\lambda +r+m)}\Lambda ^{(r,\lambda )}(\log V_{B},\log V_{B}) = \frac{1}{\Phi (r)} \left (\Big( \frac{V_{B}}{V_{T}} \Big)^{\Phi (r)}\wedge 1\right ). \end{aligned}$$

From Remark 3.1, 1) and (C.12), we can conclude that for \(q\geq 0\),

$$\begin{aligned} &\frac{\lambda +r+m }{\Phi (\lambda +r+m)} \big(1-J^{(q, \lambda )}(0;1) \big) \\ &= \frac{\lambda +r+m }{\Phi (\lambda +r+m)} \frac{\psi (1)-{q}}{\lambda +{q}-\psi (1)} \frac{\Phi ({q}+\lambda )-1}{1-\Phi ({q})} \xrightarrow{\lambda \uparrow \infty }\frac{\psi (1)-q}{1-\Phi (q)}. \end{aligned}$$

Combining these and (4.2), we obtain (4.8).  □

C.6 Proof of Proposition 6.1

Fix \(t > 0\). Let us define the event

$$\begin{aligned} E := \{ N^{\lambda }_{t} = 1 \} = \{ T^{\lambda }_{1} \leq t, T^{ \lambda }_{2} > t \} = \{ T^{\lambda }_{1} \leq t, S > t - T^{\lambda }_{1} \}, \end{aligned}$$

where \(S := T^{\lambda }_{2} - T^{\lambda }_{1}\) has an exponential distribution with parameter \(\lambda \). Note that

$$\begin{aligned} E \cap \{ T_{V_{B}}^{-} < t \} = \{ T^{\lambda }_{1}\leq t, \, V_{T^{ \lambda }_{1}}< V_{B}, \; S> t-T^{\lambda }_{1} \}. \end{aligned}$$

We start by analysing the numerator of (6.2). We decompose it as

$$\begin{aligned} f(t):= \mathbb{E}\big[\big(P-(1-\alpha )V_{T_{V_{B}}^{-}} \big) e^{-r T_{V_{B}}^{-}} \mathbf{1}_{\{T_{V_{B}}^{-} \leq t\}} \big]&= f_{1}(t) + f_{2}(t), \end{aligned}$$


$$\begin{aligned} f_{1}(t) &:= \mathbb{E}\big[\big(P-(1-\alpha )V_{T_{V_{B}}^{-}} \big)e^{-r T_{V_{B}}^{-}}\mathbf{1}_{\{T_{V_{B}}^{-} \leq t\}} \, \mathbf{1}_{E} \big], \\ f_{2}(t) &:=\mathbb{E}\big[\big(P-(1-\alpha )V_{T_{V_{B}}^{-}} \big) e^{-r T_{V_{B}}^{-}}\mathbf{1}_{\{T_{V_{B}}^{-} \leq t\}} \, \mathbf{1}_{E^{c}} \big]. \end{aligned}$$

Here, by (C.13) and because \(S\) is an independent exponential random variable with parameter \(\lambda \),

$$\begin{aligned} f_{1}(t)&=\mathbb{E}\big[\big( P-(1-\alpha )V_{T^{\lambda }_{1}} \big) e^{-r T^{\lambda }_{1}}\mathbf{1}_{\{T^{\lambda }_{1}\leq t, \, V_{T^{\lambda }_{1}}< V_{B}, \; S>t-T^{\lambda }_{1}\}}\big] \\ &=\mathbb{E}\big[\big( P-(1-\alpha )V_{T^{\lambda }_{1}} \big) e^{-r T^{ \lambda }_{1}}e^{-\lambda (t-T^{\lambda }_{1}) }\mathbf{1}_{\{T^{ \lambda }_{1}\leq t, \, V_{T^{\lambda }_{1}}< V_{B}\}}\big] \\ &=\mathbb{E}\bigg[\int _{0}^{t}\lambda e^{-\lambda s}\big(P-(1- \alpha )V_{s} \big) e^{-r s}e^{-\lambda (t-s) } \mathbf{1}_{\{V_{s}< V_{B} \}}{\mathrm{d}}s \bigg] \\ &=\lambda e^{-\lambda t} \mathbb{E} \bigg[\int _{0}^{t}\big( P-(1- \alpha )V_{s} \big) e^{-r s} \mathbf{1}_{\{V_{s}< V_{B}\}}{\mathrm{d}}s \bigg], \end{aligned}$$

and \(|f_{2}(t)| \leq (|P|+(1-\alpha )V_{B}) \mathbb{P} [ N_{t}^{\lambda }\geq 2] =o(t)\) as \(t \downarrow 0\). Summing \(f_{1}(t)\) and \(f_{2}(t)\),

$$\begin{aligned} f(t) =\lambda e^{-\lambda t}\mathbb{E}\bigg[\int _{0}^{t}\big( P-(1- \alpha )V_{s} \big) e^{-r s} \mathbf{1}_{\{V_{s}< V_{B}\}}{\mathrm{d}}s \bigg]+o(t). \end{aligned}$$

On the other hand, we transform the denominator of (6.2) as

$$\begin{aligned} g(t):= \mathbb{E} \big[1- e^{-r(t\wedge T_{V_{B}}^{-})}\big]=1-e^{-rt}+ g_{1}(t) + g_{2}(t), \end{aligned}$$


$$\begin{aligned} g_{1}(t) &:= \mathbb{E}\big[(e^{-rt}-e^{-rT_{V_{B}}^{-}})\mathbf{1}_{ \{T_{V_{B}}^{-}\leq t\}} \mathbf{1}_{E} \big], \\ g_{2}(t) &:= \mathbb{E}\big[(e^{-rt}-e^{-rT_{V_{B}}^{-}})\mathbf{1}_{ \{T_{V_{B}}^{-}\leq t\}} \mathbf{1}_{E^{c}} \big]. \end{aligned}$$

Similarly to the computation for \(f_{1}(t)\) and \(f_{2}(t)\), by (C.13),

$$\begin{aligned} g_{1}(t)&= \mathbb{E}\big[(e^{-rt}-e^{-rT^{\lambda }_{1}})\mathbf{1}_{ \{T^{\lambda }_{1}\leq t, \, V_{T^{\lambda }_{1}}< V_{B}, \, S > t-T^{ \lambda }_{1}\}}\big] \\ &=\mathbb{E}\big[e^{-\lambda (t-T^{\lambda }_{1})}(e^{-rt}-e^{-rT^{ \lambda }_{1}})\mathbf{1}_{\{T^{\lambda }_{1}\leq t, \, V_{T^{\lambda }_{1}}< V_{B} \}}\big] \\ &= \lambda e^{-\lambda t}\mathbb{E}\bigg[\int _{0}^{t}(e^{-rt}-e^{-rs}) \mathbf{1}_{\{V_{s}< V_{B}\}}{\mathrm{d}}s\bigg], \end{aligned}$$

and \(g_{2}(t) \leq \mathbb{P} [N_{t}^{\lambda }\geq 2] = o(t)\). Hence putting all the pieces together, we get that

$$\begin{aligned} g(t) =1-e^{-rt}+ \lambda e^{-\lambda t}\mathbb{E}\left [\int _{0}^{t}(e^{-rt}-e^{-rs}) \mathbf{1}_{\{V_{s}< V_{B}\}}{\mathrm{d}}s\right ]+o(t). \end{aligned}$$

Now from (C.14), (C.15) and the mean value theorem,

$$\begin{aligned} \lim _{t\to 0}\frac{f(t)}{t} &=\lim _{t\to 0}\frac{1}{t}\bigg( \lambda e^{-\lambda t}\mathbb{E}\bigg[\int _{0}^{t}\big( P-(1-\alpha )V_{s} \big) e^{-r s} \mathbf{1}_{\{V_{s}< V_{B}\}}{\mathrm{d}}s \bigg]+o(t)\bigg) \\ &=\lambda \big( P-(1-\alpha )V\big) \mathbf{1}_{\{V< V_{B}\}}, \\ \lim _{t\to 0}\frac{g(t)}{t} &=\lim _{t\to 0}\frac{1}{t}\bigg(1-e^{-rt}+ \lambda e^{-\lambda t}\mathbb{E}\bigg[\int _{0}^{t}(e^{-rt}-e^{-rs}) \mathbf{1}_{\{V_{s}< V_{B}\}}{\mathrm{d}}s\bigg]+o(t)\bigg) \\ &=r. \end{aligned}$$

By dividing the first by the second limit, we have the claim. □

C.7 Proof of Proposition 6.2

By (3.5) and (3.7), we can write for any \(\theta \geq 0\) and \(q \geq 0\) that

$$\begin{aligned} &J^{(q, \lambda )}(y;\theta ) \\ &=\frac{\lambda }{\lambda +q-\psi (\theta )}\bigg(H^{(q)}(y;\theta )- \frac{\psi (\theta )-q}{\lambda } \frac{\Phi (q+\lambda )-\Phi (q)}{\theta -\Phi (q)}H^{(q)}\big(y; \Phi (q+\lambda )\big)\bigg). \end{aligned}$$

For \(y\neq0\), we now note the following:

1) For the cases (i) \(y < 0\) or (ii) \(y > 0\) and \(X\) does not have a diffusion component, we have that \(H^{(q)}(y;\Phi (q+\lambda )) \xrightarrow{\lambda \uparrow \infty } 0 \) (because the process does not creep downward as in Kyprianou [36, Exercise 7.6]) and \(\frac{\Phi (q+\lambda )-\Phi (q)}{\lambda }\) is bounded for \(\lambda \ge \delta >0\) (which can be verified by the convexity of \(\psi \)).

2) For the case where \(y > 0\) and \(X\) has a diffusion component,

$$ H^{(q)}\big(y;\Phi (q+\lambda )\big) \xrightarrow{\lambda \uparrow \infty } \mathbb{E}_{y} \big[e^{-q \tau _{0}^{-}} \mathbf{1}_{\{X_{\tau _{0}^{-}} = 0, \tau _{0}^{-} < \infty \}}\big] $$

and \(\frac{\Phi (q+\lambda )-\Phi (q)}{\lambda } \xrightarrow{\lambda \uparrow \infty } 0\) (because \(\psi (\theta ) \sim \frac{1}{2} \sigma ^{2} \theta ^{2}\) as \(\theta \rightarrow \infty \), where \(\sigma \) is the diffusion coefficient of \(X\)). Hence the previous arguments imply that for \(y \neq 0\),

$$\begin{aligned} \lim _{\lambda \to \infty } J^{(q, \lambda )}(y;\theta )=H^{(q)}(y; \theta ),\qquad \theta \geq 0. \end{aligned}$$

Given that \(J^{(q, \lambda )}(y;\theta )\) is the Laplace transform of the random vector \((\tilde{T}_{0}^{-} (\lambda ) ,X_{\tilde{T}_{0}^{-}(\lambda )})\) (where we put \((\lambda )\) to spell out the dependence on \(\lambda \)), Lévy’s continuity theorem implies that \((\tilde{T}_{0}^{-} (\lambda ) ,X_{\tilde{T}_{0}^{-}}(\lambda ))\) converges in distribution to \((\tau _{0}^{-},X_{\tau _{0}^{-}})\). Hence using Skorohod’s representation theorem (see Billingsley [13, Theorem 6.7]) as well as dominated convergence, we obtain for \(V \neq V_{B}\) that

$$\begin{aligned} \lim _{\lambda \to \infty }\mathrm{CS}_{\lambda }(t)&=\frac{r}{P}\lim _{ \lambda \to \infty } \frac{\mathbb{E}_{\log (V/V_{B})} [ (P-(1-\alpha )V_{B} e^{X_{\tilde{T}_{0}^{-}(\lambda )}} ) e^{-r \tilde{T}_{0}^{-}(\lambda )}\mathbf{1}_{\{\tilde{T}_{0}^{-}(\lambda )\leq t\}} ]}{\mathbb{E}_{\log (V/V_{B})} [1- e^{-r(t\wedge \tilde{T}_{0}^{-}(\lambda ))} ]} \\ &=\frac{r}{P} \frac{\mathbb{E}_{\log (V/V_{B})} [ (P-(1-\alpha )V_{B} e^{X_{\tau _{0}^{-}}} ) e^{-r \tau _{0}^{-}}\mathbf{1}_{\{\tau _{0}^{-}\leq t\}} ]}{\mathbb{E}_{\log (V/V_{B})} [1- e^{-r(t\wedge \tau _{0}^{-})} ]}= \mathrm{CS}(t). \end{aligned}$$


Appendix D: Proof of Theorem B.1

From Kuznetsov et al. [35, Theorem 2.7], for any Borel set \(A\) in \([0, \infty )\), in ℝ and in \((-\infty ,0]\), respectively, we have

$$\begin{aligned} &\mathbb{E}_{x} \bigg[ \int _{0}^{\tau _{0}^{-} } e^{-qt} \mathbf{1}_{ \left \{ X_{t} \in A \right \} } {\mathrm{d}}t\bigg] \\ &= \int _{A} \big( e^{-\Phi (q) y}W^{(q)}(x) -{W^{(q)}} (x-y) \big) { \mathrm{d}}y, \qquad x \geq 0, \end{aligned}$$
$$\begin{aligned} &\mathbb{E}_{x}\bigg[ \int _{0}^{\infty }e^{-(q+\lambda )t } \mathbf{1}_{\{X_{t} \in A\}}{\mathrm{d}}t\bigg] \\ &=\int _{A} \bigg( \frac{e^{\Phi (q+\lambda )(x-y)}}{\psi '(\Phi (q+\lambda )) }-W^{(q+\lambda )}(x-y)\bigg) \mathrm{d}y, \qquad x \in \mathbb{R}, \end{aligned}$$
$$\begin{aligned} &\mathbb{E}_{x} \bigg[ \int _{0}^{\tau _{0}^{+} } e^{-(q+\lambda )t} \mathbf{1}_{ \{ X_{t} \in A \}} {\mathrm{d}}t\bigg] \\ &= \int _{A} \big(e^{\Phi (q+\lambda )x}W^{(q+\lambda )}(-y)-W^{(q+ \lambda )}(x-y)\big) \mathrm{d}y, \qquad x \leq 0, \end{aligned}$$

where \(\tau _{0}^{-}\) is defined in (3.4) and \(\tau _{0}^{+}:=\inf \{t\geq 0: X_{t}>0\}\).

We prove the result for \(z=0\) and compute

$$\begin{aligned} g(x) :=\mathbb{E}_{x}\bigg[ \int _{0}^{\tilde{T}_{0}^{-} } e^{-qt} h(X_{t}) \mathrm{d}t \bigg], \qquad x \in \mathbb{R}. \end{aligned}$$

The general case follows because the spatial homogeneity of the Lévy process implies that \(\mathbb{E}_{x} [ \int _{0}^{\tilde{T}_{z}^{-} } e^{-qt} h(X_{t}) { \mathrm{d}}t ] =\mathbb{E}_{x-z} [ \int _{0}^{\tilde{T}_{0}^{-}} e^{-qt} h (X_{t}+z) \mathrm{d}t ]\) for \(x,z\in \mathbb{R}\).

For \(x \in \mathbb{R}\), by the strong Markov property,

$$\begin{aligned} g(x)&=\mathbb{E}_{x}\bigg[ \int _{0}^{\tau _{0}^{-} } e^{-qt} h(X_{t}) \mathrm{d}t \bigg] + \mathbb{E}_{x}\big[ e^{-q\tau _{0}^{-}}g(X_{\tau ^{-}_{0}}) \mathbf{1}_{\{ \tau ^{-}_{0}< \infty \}} \big]. \end{aligned}$$

In particular, for \(x < 0\), again by the strong Markov property,

$$\begin{aligned} g(x) = A(x) g(0)+B(x), \end{aligned}$$

where for \(x \leq 0\),

$$\begin{aligned} A(x)&:=\mathbb{E}_{x} \big[ e^{-q \tau _{0}^{+}} \mathbf{1}_{\{ \tau ^{+}_{0}< T_{1}^{\lambda }\}} \big] =\mathbb{E}_{x} \big[ e^{-(q+ \lambda ) \tau _{0}^{+}} \big] = e^{\Phi (q+\lambda )x}, \\ B(x)&:=\mathbb{E}_{x} \bigg[ \int _{0}^{\tau _{0}^{+}} e^{-qt} \mathbf{1}_{\{ t < T_{1}^{\lambda }\}} h(X_{t}) \mathrm{d}t\bigg] \\ &\phantom{:}=\int _{-\infty }^{0} h(y) \big(e^{\Phi (q+\lambda )x}W^{(q+\lambda )}(-y)-W^{(q+ \lambda )}(x-y)\big) \mathrm{d}y. \end{aligned}$$

Here the first equality for \(A(x)\) holds by the fact that \(T_{1}^{\lambda }\) is an independent exponential random variable with parameter \(\lambda \) and Kyprianou [36, Theorem 3.12]. The equality for \(B(x)\) is a consequence of (D.3).

Now by (3.5),

$$ \mathbb{E}_{x}\big[e^{-q\tau _{0}^{-}}A(X_{\tau _{0}^{-}})\mathbf{1}_{ \{\tau _{0}^{-}< \infty \}}\big]=H^{(q)}\big(x;\Phi (q+\lambda )\big), \qquad x \in \mathbb{R}, $$

for the function \(H^{(q)}\) defined in (3.5). In addition, by Pérez et al. [50, proof of Theorem 4.1], we have

$$\begin{aligned} \mathbb{E}_{x}\big[e^{-q\tau _{0}^{-}}B(X_{\tau _{0}^{-}})\mathbf{1}_{ \{\tau _{0}^{-}< \infty \}}\big] &=W^{(q)}(x)\int _{-\infty }^{0} h(y) H^{(q+ \lambda )}\big(-y; \Phi (q)\big) \mathrm{d}y \\ &\phantom{=:}-\int _{-\infty }^{0} h(y) I^{(q, \lambda )}(x,-y) \mathrm{d}y. \end{aligned}$$

Substituting these in (D.4) and then applying (D.1) and [50, Remark 4.3], we obtain for all \(x \in \mathbb{R}\) that

$$\begin{aligned} g(x) &= g(0)H^{(q)}\big(x;\Phi (q+\lambda )\big) +W^{(q)}(x)\int _{- \infty }^{\infty }h(y) H^{(q+\lambda )}\big(-y; \Phi (q)\big) \mathrm{d}y \\ &\phantom{=:}-\int _{-\infty }^{\infty }h(y) I^{(q, \lambda )}(x,-y) \mathrm{d}y. \end{aligned}$$

On the other hand, by the strong Markov property, we can also write

$$\begin{aligned} g(0) &= \mathbb{E}_{0} \bigg[ \mathbb{E}_{0}\Big[ \int _{0}^{T_{1}^{\lambda }} e^{-qt} h(X_{t}) \mathrm{d}t \\ &\phantom{=}\qquad \qquad \quad + \mathbf{1}_{\{X_{T_{1}^{\lambda }} > 0 \}}\int _{T_{1}^{\lambda }}^{\tilde{T}_{0}^{-} } e^{-qt} h(X_{t}) \mathrm{d}t \Big| T_{1}^{\lambda }, (X_{u})_{0 \leq u \leq T_{1}^{\lambda }}\Big] \bigg] \\ &= \gamma _{1} + \gamma _{2}, \end{aligned}$$


$$ \gamma _{1} := \mathbb{E}_{0} \bigg[\int _{0}^{T_{1}^{\lambda }} e^{-qt} h(X_{t}) \mathrm{d}t \bigg], \qquad \gamma _{2} := \mathbb{E}_{0} \big[e^{-q T_{1}^{\lambda }} g(X_{T_{1}^{\lambda }}) \mathbf{1}_{\{ X_{T_{1}^{\lambda }} > 0\}} \big]. $$

We compute \(\gamma _{1}\) and \(\gamma _{2}\) below. First observe that

$$ \gamma _{1} = \mathbb{E}_{0} \left [\int _{0}^{\infty }\mathbf{1}_{\{t < T_{1}^{\lambda }\}}e^{-qt} h(X_{t}) \mathrm{d}t \right ] = \mathbb{E}_{0} \left [\int _{0}^{\infty } e^{-(q+\lambda ) t} h(X_{t}) \mathrm{d}t \right ]. $$

For \(\gamma _{2}\), by (D.2), we can write

$$\begin{aligned} \gamma _{2} &=\lambda \mathbb{E}_{0} \bigg[\int _{0}^{\infty }e^{-(q+ \lambda )s}g(X_{s}) \mathbf{1}_{\{ X_{s} > 0\}}{\mathrm{d}}s\bigg] \\ &=\frac{\lambda }{\psi '(\Phi (q+\lambda ))}\int _{0}^{\infty } e^{- \Phi (q+\lambda )y}g(y)\mathrm{d}y, \end{aligned}$$

which we compute by using the expression of \(g\) in (D.5). First, by [50, identity (A.8)], we have

$$\begin{aligned} \begin{aligned} \int _{0}^{\infty }e^{-\Phi (q+\lambda )y}Z^{(q)}\big(y;\Phi (q+ \lambda )\big)\mathrm{d}y=\frac{\psi '(\Phi (q+\lambda ))}{\lambda }, \end{aligned} \end{aligned}$$

while (3.3) gives \(\int _{0}^{\infty }e^{-\Phi (q+\lambda ) y} W^{(q)}(y) \mathrm{d}y = \lambda ^{-1}\), and therefore

$$\begin{aligned} \int _{0}^{\infty }e^{-\Phi (q+\lambda )y}H^{(q)}\big(y;\Phi (q+ \lambda )\big)\mathrm{d}y=\frac{\psi '(\Phi (q+\lambda ))}{\lambda }- \frac{1}{\Phi (q+\lambda )-\Phi (q)}. \end{aligned}$$

Again by [50, proof of Theorem 4.1], we have

$$\begin{aligned} &\int _{0}^{\infty }e^{-\Phi (q+\lambda )y}\int _{-\infty }^{\infty }h(z) I^{(q, \lambda )}(y,-z) \mathrm{d}z \mathrm{d}y \\ &=\frac{\psi '(\Phi (q+\lambda ))}{\lambda } \mathbb{E}_{0} \left [ \int _{0}^{\infty }e^{-(q+\lambda )t}h(X_{t}) \mathrm{d}t \right ]. \end{aligned}$$

Substituting these in (D.7) and with the help of (D.5),

$$\begin{aligned} \gamma _{2} &=g(0)\frac{\lambda }{\psi '(\Phi (q+\lambda ))}\bigg( \frac{\psi '(\Phi (q+\lambda ))}{\lambda }- \frac{1}{\Phi (q+\lambda )-\Phi (q)}\bigg) \\ &\phantom{=:}- \mathbb{E}_{0} \left [\int _{0}^{\infty }e^{-(q+\lambda )t}h(X_{t}){ \mathrm{d}}t \right ] \\ &\phantom{=:}+\frac{1}{\psi '(\Phi (q+\lambda ))} \int _{-\infty }^{\infty }h(y) H^{(q+ \lambda )}\big(-y; \Phi (q)\big) \mathrm{d}y. \end{aligned}$$

Now substituting the computed values of \(\gamma _{1}\) and \(\gamma _{2}\) in (D.6), we obtain

$$\begin{aligned} g(0) &=g(0)- \frac{\lambda }{\Phi (q+\lambda )- \Phi (q)} \frac{g(0)}{\psi '(\Phi (q+\lambda ))} \\ &\phantom{=:}+\frac{1}{\psi '(\Phi (q+\lambda ))}\int _{-\infty }^{\infty }h(y) H^{(q+ \lambda )}\big(-y; \Phi (q)\big) \mathrm{d}y, \end{aligned}$$

and hence solving for \(g(0)\), we obtain

$$\begin{aligned} g(0)= \frac{\Phi (q+\lambda )- \Phi (q)}{\lambda } \int _{-\infty }^{\infty }h(y) H^{(q+\lambda )}\big(-y; \Phi (q)\big) \mathrm{d}y. \end{aligned}$$

Substituting this back in (D.5), we have

$$\begin{aligned} g(x)&=Z^{(q)}\big(x;\Phi (q+\lambda )\big) \frac{\Phi (q+\lambda )- \Phi (q)}{\lambda } \int _{-\infty }^{\infty }h(y) H^{(q+\lambda )}\big(-y; \Phi (q)\big)\mathrm{d}y \\ &\phantom{=:}-\int _{-\infty }^{\infty }h(y) I^{(q, \lambda )}(x,-y) \mathrm{d}y. \end{aligned}$$

Hence the resolvent density is given by (B.2), as claimed.  □

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Palmowski, Z., Pérez, J.L., Surya, B.A. et al. The Leland–Toft optimal capital structure model under Poisson observations. Finance Stoch 24, 1035–1082 (2020).

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  • Credit risk
  • Endogenous bankruptcy
  • Optimal capital structure
  • Spectrally negative Lévy processes
  • Term structure of credit spreads

Mathematics Subject Classification (2010)

  • 60G40
  • 60G51
  • 91G40

JEL Classification

  • C61
  • G32
  • G33