Abstract
Recent empirical studies suggest that the volatilities associated with financial time series exhibit short-range correlations. This entails that the volatility process is very rough and its autocorrelation exhibits sharp decay at the origin. Another classic stylistic feature often assumed for the volatility is that it is mean reverting. In this paper it is shown that the price impact of a rapidly mean reverting rough volatility model coincides with that associated with fast mean reverting Markov stochastic volatility models. This reconciles the empirical observation of rough volatility paths with the good fit of the implied volatility surface to models of fast mean reverting Markov volatilities. Moreover, the result conforms with recent numerical results regarding rough stochastic volatility models. It extends the scope of models for which the asymptotic results of fast mean reverting Markov volatilities are valid. The paper concludes with a general discussion of fractional volatility asymptotics and their interrelation. The regimes discussed there include fast and slow volatility factors with strong or small volatility fluctuations and with the limits not commuting in general. The notion of a characteristic term structure exponent is introduced, this exponent governs the implied volatility term structure in the various asymptotic regimes.
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Acknowledgements
This research has been supported in part by Centre Cournot, Fondation Cournot, and Université Paris Saclay (chaire D’Alembert).
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Appendices
Technical lemmas
We denote
The martingale \(\psi ^\varepsilon _t\) defined by (33) has the form
Lemma 2
\((\psi _t^\varepsilon )_{t\in [0,T]}\) is a square-integrable martingale and
Proof
See Lemma B.1 in Garnier and Sølna (2016). \(\square \)
The important properties of the random process \(\vartheta ^\varepsilon _{t}\) are stated in the following lemma.
Lemma 3
-
1.
The exists a constant \(K_T\) such that, for any \(t \in [0,T]\), we have almost surely
$$\begin{aligned} \big | \sigma _t^\varepsilon \vartheta ^\varepsilon _{t} \big | \le K_T \varepsilon ^{1/2} . \end{aligned}$$(57) -
2.
For any \(t \in [0,T]\), we have
$$\begin{aligned} \mathbb {E}[ \sigma _t^\varepsilon \vartheta ^\varepsilon _{t} ] = \varepsilon ^{1/2} \overline{D} + \widetilde{D}^\varepsilon _{t}, \end{aligned}$$(58)where \( \overline{D}\) is the deterministic constant (27) and \(\widetilde{D}^\varepsilon _{t}\) is smaller than \(\varepsilon ^{1/2}\):
$$\begin{aligned} \sup _{\varepsilon \in (0,1]} \sup _{t \in [0,T]} \varepsilon ^{-1/2} \big | \widetilde{D}^\varepsilon _{t}\big | < \infty , \end{aligned}$$(59)and
$$\begin{aligned} \forall t \in [0,T),\quad \lim _{\varepsilon \rightarrow 0} \varepsilon ^{-1/2} \big | \widetilde{D}^\varepsilon _{t}\big | =0. \end{aligned}$$(60) -
3.
For any \(0\le t< t' < T\), we have
$$\begin{aligned} \lim _{\varepsilon \rightarrow 0} \varepsilon ^{-1} \big | \mathrm{Cov} \big ( \sigma _t^\varepsilon \vartheta ^\varepsilon _{t},\sigma _{t'}^\varepsilon \vartheta ^\varepsilon _{t'}\big ) \big | =0. \end{aligned}$$(61)
Proof
Using the expression (56) of \(\vartheta ^\varepsilon _t\):
The proof of the first item follows from the fact that \(\mathcal{K}^\varepsilon (t)=\mathcal{K}(t/\varepsilon )/\sqrt{\varepsilon }\), \(\mathcal{K} \in L^1(0,\infty )\).
The expectation of \( \sigma _t^\varepsilon \vartheta ^\varepsilon _{t} \) is equal to
with \(p_C\) defined in Proposition 1.
Therefore the difference
can be bounded by
which gives the second item since \(\mathcal{K} \in L^1(0,\infty )\).
Let us consider \(0 \le t \le t'\le T\). We have
so we can write
and therefore
We can write for any \(\tau >t\):
where \(A^\varepsilon _{t\tau }\) is \(\mathcal{F}_t\) adapted while \(B^\varepsilon _{t\tau }\) is independent from \(\mathcal{F}_t\). Therefore (\(s'\ge t'\ge t\))
where \((\tilde{A}^\varepsilon _{tt'} , \tilde{B}^\varepsilon _{tt'}, \tilde{A}^\varepsilon _{ts'} , \tilde{B}^\varepsilon _{ts'})\) is an independent copy of \(({A}^\varepsilon _{tt'} , {B}^\varepsilon _{tt'}, {A}^\varepsilon _{ts'} , {B}^\varepsilon _{ts'})\). We can then write
where we used Lemma 7 in the last inequality. Then, using the fact that \(\mathcal{K}\in L^1\), this gives
which proves the third item.
Lemma 4
For any smooth function f with bounded derivative, we have
Proof
The conditional distribution of \(Z_t^\varepsilon \) given \(\mathcal{F}_0\) is Gaussian with mean
and variance
Therefore
where p(z) is the pdf of the standard normal distribution. The random variable \(\mathbb {E}\big [ Z_{t}^\varepsilon |\mathcal{F}_0 \big ] \) is Gaussian with mean zero and variance \((\sigma _{t,\infty }^\varepsilon )^2\) so that
which is the desired result.
The random term \(\phi ^\varepsilon _{t}\) defined by (32) has the form
with G defined in (54).
Lemma 5
For any \(t \le T\), \(\phi _{t}^\varepsilon \) is a zero-mean random variable with standard deviation of order \(\varepsilon ^{1-H}\):
Proof
For \(t\in [0,T]\) the second moment of \(\phi _{t}^\varepsilon \) is:
We have by Lemma 4
In view of Lemma 7 we then have
uniformly in \(t \le T\) and \(\varepsilon \in (0,1]\) for some constant \(C_{T}\).
Lemma 6
Let us define for any \(t \in [0,T]\):
as in (41). We have
Proof
Since the expectation \(\mathbb {E}[ G(Z^\varepsilon _0)]=0\), we have
We have moreover
By Lemma 4 we obtain
In view of Lemma 7 we then have
uniformly in \(t \in [0,T]\) and \(\varepsilon \in (0,1]\), which gives the desired result.
Lemma 7
Define
Then there exists \(C>0\) such that
Proof
This follows from \(|\mathcal{K}(s)| \le K s^{H-\frac{3}{2}}\) for \(s \ge 1\) and \(\mathcal{K}\in L^2\).
An alternative model
In Comte and Renault (1998); Funahashi and Kijima (2017) the authors consider a stochastic volatility model that is a kind of fractional Orstein-Uhlenbeck process, but they consider the following representation of the fractional Brownian motion:
where \((W^0_t)_{t \in \mathbb {R}^+}\) is a standard Brownian motion over \(\mathbb {R}^+\). \((W^{H,0}_t)_{t \in \mathbb {R}^+}\) is a zero-mean self-similar Gaussian process, in the sense that \((\alpha ^H W^{H,0}_{t/\alpha })_{t \in \mathbb {R}^+} \) and \((W_t^{H,0})_{t \in \mathbb {R}^+}\) have the same distribution, but it is not stationary, nor does it have stationary increments. Its variance is
while the variance of its increment is (for \(s>0\)):
which has the following behavior
This model is special because time zero plays a special role, and we think it is desirable to deal with the stationary situation addressed in this paper. However, it turns out that the two models give the same result in the fast-varying case. Indeed, the modified fOU process corresponding to (70) is [to be compared with (4)]:
where \(Z_0\) is considered as a constant as in Comte and Renault (1998), Funahashi and Kijima (2017). In terms of the Brownian motion \(W^0_t\) this reads:
where \(\mathcal{K}^\varepsilon \) is defined in (10). It is a Gaussian process with the following covariance (\(t,s\ge 0\)):
that is a function of \(t/\varepsilon \) and \(s/\varepsilon \) with
Note that
with \(\mathcal{C}_Z\) defined by (6). In other words, except for a small period of time just after time 0 which is of duration of the order of \(\varepsilon \), the modified process has the same behavior as the one introduced in this paper. One can then check the detailed calculations carried out in this paper and find that Proposition 1 still holds true with the modified model \(Z^{\varepsilon ,0}_t\).
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Garnier, J., Sølna, K. Option pricing under fast-varying and rough stochastic volatility. Ann Finance 14, 489–516 (2018). https://doi.org/10.1007/s10436-018-0325-4
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DOI: https://doi.org/10.1007/s10436-018-0325-4
Keywords
- Stochastic volatility
- Short-range correlation
- Fractional Ornstein–Uhlenbeck process
- Hurst exponent
- Mean reversion