Abstract
Return on Investment (ROI) is widely regarded as a key measure of firm profitability. The accounting literature has long recognized that ROI will generally not reflect economic profitability, as determined by the internal rate of return (IRR) of a firm’s investment projects. In particular, it has been noted that accounting conservatism may result in an upward bias of ROI, relative to the underlying IRR. We examine both theoretically and empirically the behavior of ROI as a function of two variables: past growth in new investments and accounting conservatism. Higher growth is shown to result in lower levels of ROI provided the accounting is conservative, while the opposite is generally true for liberal accounting policies. Conversely, more conservative accounting will increase ROI provided growth in new investments has been “moderate” over the relevant horizon, while the opposite is true if new investments grew at sufficiently high rates. Taken together, we find that conservatism and growth are “substitutes” in their joint impact on ROI.
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Notes
For instance, Scherer (1982) cites abnormally high ROAs in the breakfast cereal industry as a rationale for why the Federal Trade Commission intervened in that industry. Similarly, in the recent discussion about “excessive profits” in the oil refining industry, commentators frequently cite evidence based on ROI data. Some organizations, like the OECD, have also used ROI measures for country-wide comparisons of profitability; see, for instance, Chan-Lee and Sutch (1985).
Feltham and Ohlson (1996), Ohlson and Zhang (1998) and Zhang (2000) refer to accounting as conservative if on average market values exceed book values. In contrast, Basu (1997) and Watts (2003) emphasize asymmetry in the recognition of anticipated losses as opposed to the non-recognition of anticipated gains.
A central question in the industrial organization literature is whether in the long run firm profits tend to revert to competitive levels. To answer this question, a variety of profit measurement methodologies have been developed; see, for instance, Mueller (1986) and Stark (2004). Some authors, including Fisher and McGowan (1983), have argued that it is generally impossible to infer economic profitability from reported accounting rates of return. Our perspective in this paper is to explore how the key variables of growth and conservatism shift the accounting rate of return relative to the underlying economic rate of return.
This representation of conservatism is equivalent to the criterion that at each point in time the fair market value of a firm’s projects exceeds the book value (Feltham and Ohlson 1996; Zhang 2000). In the language of Beaver and Ryan (2004), we consider unconditional conservatism, in contrast to the conditional, i.e., event-dependent, conservatism of Basu (1997) and others.
These predictions are related to the work of Lev et al. (2005) who examine whether expensing of R&D tends to generate conservative or aggressive performance measures.
For ease of notation, we initially do not consider the possibility of immediate (partial) expensing of new investments. Our model is expanded in Sect. 1.4 so as to include this possibility. It is readily checked that the results derived in this subsection and the next are unaffected if one allows for partial expensing.
One can interpret our setting as one where all free cash flows obtained in previous periods were paid out as dividends.
ROI cannot be either consistently above or consistently below the internal rate of return, for otherwise the present value of the associated residual incomes, with the capital charge rate given by r, could not be zero.
All proofs are provided in Appendix A.
The word “fair” is put in quotation marks here because future cash flows are discounted at the internal rate of return r, rather than some exogenously given cost of capital.
Gjesdal (2004) also notes that even with constant growth ROI T (λ) may not be a decreasing function of λ.
If one imposes the stronger condition of neo-conservatism and assumes that annual growth is constant, i.e., λ = λ t , then the “quadrant” result of Proposition 1 follows from the following simple argument: ROI T (λ) ≥ r is equivalent to \({\sum^{T}_{t=1} RI^{o}_t \cdot (1+\lambda)^{T-t}\ge 0}\). We know that this inequality holds as an equality at λ = r. If the sequence RI o t is monotone increasing, it will change sign once and therefore Descartes’ “rule of signs” yields the conclusion.
In the literature on managerial performance evaluation, Rogerson (1997) and others have advocated the so-called relative benefit depreciation rule as a means of creating goal congruence between owners and managers. As observed in Reichelstein (1997) and Dutta and Reichelstein (2005), relative benefit depreciation amounts to conservative accounting. It is essential to recall, however, that in these models the IRR of the project is unknown to the designer of the residual income performance measure. Instead the designer seeks to motivate the better informed manager to accept those projects for which IRR exceeds the owner’s cost of capital, r c . As a consequence, it is generally impossible to attain neutral accounting. However, for zero-NPV projects, i.e., when r = r c , relative benefit depreciation does indeed result in neutral accounting. In these models, conservatism therefore does not result from an inherent conservatism bias in the depreciation schedule but from information asymmetry about the underlying project profitability.
Penman (2003) refers to the release of “hidden reserves” as growth slows.
Variants of this equation can be found in Skogsvik (1998) and Danielson and Press (2003). The latter authors also claim (on p. 510) that the derivative of ROI T (λ) with respect to λ is given by \({1- \frac{MV_{T-1}}{BV_{T-1}}}.\) We contend that this is not true, as the ratio \({\frac{MV_{T-1}}{BV_{T-1}}}\) itself is generally a function of the growth rate λ. In a different setting, Ohlson and Gao (2006) also derive Eq. (4) under the assumption that future abnormal (residual) earnings grow at a constant rate.
When T = ∞, one obtains the familiar declining balance method, provided 0 < δ < 1 and \({d_t = \delta \cdot AV^{o}_{t-1}}\) . As observed in Beaver and Dukes (1974), such a depreciation policy results in neutral accounting if \({c_t= (1-\delta) \cdot c_{t-1}}\).
As a counterexample, consider T = 5 and r = 0.1. For two liberal depreciation policies, δ = −5 and δ = −4.95, it is easily seen via numerical computation that \({ROI_{T}(\lambda,-5)- ROI_{T}(\lambda,-4.95)}\) is not a monotone function of λ. It crosses 0 from below at λ = r = 0.1, increases until λ = 1.0343, and decreases thereafter.
Also, for any given λ and δ, the formulation in (5) and the above mentioned properties of h(·) imply that ROI T (λ,δ) is always increasing and convex in the internal rate of return r. Thus, regardless of the accounting policy, the choice of more profitable projects always leads to higher accounting rates of return, and does so at an increasing rate.
We have thus far not commented on the behavior of ROI in T, the useful life of the assets. Under straight line depreciation, we find that for λ > 0, ROI T (λ,0) is a non-monotonic function of T for \({\lambda \neq r}\). In particular, \({\lim_{T\rightarrow 1} ROI_{T}(\lambda,0) = \lim_{T \rightarrow \infty} ROI_{T}(\lambda,0) = r}\) and the function ROI T (λ,0) increases (decreases) in T at values of T close to 1 depending on whether λ < (>)r. A demonstration of these claims is available upon request.
Extending Definition 1, the accounting is said to be conservative if \({\sum^{t}_{i=1}d_i + \beta \ge \sum^{t}_{i=1}d_i^{\ast}}\), where \({\sum^{T}_{i=1}d_i \equiv 1-\beta}\). Lemma 1 then extends so that conservatism is equivalent to: \({-\beta \cdot b^{o} + \sum^{t}_{i=1}RI^{o}_{i}\cdot \gamma^{i} \le 0}\) for all t. For any β ≥ 0, the criterion for neo-conservatism is unchanged from that in Definition 2, i.e., the sequence of residual income numbers is required to be increasing over time. Neo-conservatism then implies conservatism for any given β ≥ 0. Also, with uniform cash flows, any combination of partial expensing and straight line depreciation for the capitalized part of the investment amounts to neo-conservative accounting.
Since our model presumed that free cash flows are paid out as dividends, it is natural to ask whether the ROE metric is affected by different dividend policies. As a “first-order” effect, we note that ROE t is invariant to a change in dividend payments at date t−1 provided the following holds: ROE t is (initially) equal to the rate of return, r and a dividend payment of Div t-1 has the following two effects: BVE t-1 is reduced by Div t-1, and at the same time income, Inc t , is reduces by r·Div t-1.
Net Operating Assets (NOA) is calculated as Operating Assets t − Operating Liabilities t . Operating Assets is total assets less cash and short-term investments (Compustat item #1 and item #32). Operating liabilities is total assets less the long and short-term portions of debt (Compustat items #9 and #34), less book value of total common and preferred equity (Compustat items #60 and #130), less minority interest (Compustat item #38).
Implicitly, we assume that the useful life of these assets is not significantly different than the average life of the capitalized assets.
Note that the current year will be referred to as t in the empirical analysis, whereas T denotes the useful life of the assets (as discussed above).
It could be argued that this measure simply measures the degree to which a firm belongs to an industry that employs a great deal of “intangible assets,” e.g., the pharmaceutical industry. We accept this criticism, but argue that this strong correlation with industry does not diminish the measure’s usefulness since these industries are ones in which there is a higher degree of conservatism. Note that our theory does not require that the degree of conservatism be relative to firms within the industry but rather across the economy.
Among the many proxies for conservatism that have been employed in the literature, the one that is closest in spirit to ours is the “C-score” of Penman and Zhang (2002). Their metric captures conservatism as a notion of reserve creation; it uses R&D expense, advertising expense and LIFO reserves and compares them to NOA to obtain a measure of the “quality” of earnings.
Although our analysis does not seek to reconcile the differences between these cost-of-capital studies, we note several points made in earlier work. Botosan and Plumlee (2005) argue that the Vuolteenaho (2002) linear decomposition approach used by Easton and Monahan (2005) may not be properly specified because of the negative relation between EM’s “preferred” metric and risk, as measured by beta or the standard deviation of returns. In contrast, Guay et al. (2005) argue that the lack of reliability of the expected return proxies in Easton and Monahan’s study warrants a different approach. Easton and Monahan (2005) argue that neither of these two studies properly deals with the assumption that realized returns are biased and noisy measures of expected returns. Note that all of these studies examine COC measures in the cross-section. In the finance literature, Pastor et al. (2006) estimate the time-series relation between market-level measures of COC and market risk analytically (using simulations) and empirically. They argue that these same measures are a valuable proxy for expected stock return and conclude that the measures are well suited to capturing time variation in expected stock market returns. Thus, the evidence on the validity of these COC measures is quite mixed and still emerging. Finally, note that all of these measures purport to capture the firm’s cost of capital, and not its internal rate of return, the difference being “abnormal profitability”.
This approach also has the advantage of dampening random variation caused by different estimation procedures; Dhaliwal et al. (2005) and Hail and Leuz (2006) use this approach as well. When all three measures are unavailable for the same firm-year observation, we take the average of as many different measures as are available to keep the sample size as large as possible.
Because of the ongoing debate regarding appropriate ways to measure the cost of capital, we also conduct a robustness check where we simply replace the cost of capital measure with 12% (Dechow et al. 2004). The results remain qualitatively unchanged.
Note that because of the requirement that PGrowth and COC deviate by 1%, MG = 1 does not imply that AG = 0.
In unreported tests, we also estimate this changes specification using first differences in Uselife, Conserv and COCfactor as the control variables instead of the levels. Results are quantitatively similar.
As indicated above, we also examine these same tests using ROA and RNOA instead of ROE, and WACC instead of COC. Our results are qualitatively similar. The coefficients on PGrowth and the current deviation from PGrowth are negative in all four specifications.
We do not estimate rank regressions for this particular empirical specification. The process of creating decile ranks after squaring is ordinal because it preserves the monotonic relationship. Squaring a variable is a simple monotonic transformation and recall that this is the primary attribute of rank regressions (Iman and Conover 1979). Thus, the rank variable will have the exact values as the primary value after decile ranking and adds no new information or variation to the regression estimation.
We find similar results when estimating this regression using RNOA. However, we do not obtain statistically significant results when using ROA.
In unreported tests, when using ROA instead of ROE, ρ1 and ρ5 are negative and statistically significant in both of the empirical specifications. Further, the results are larger in economic significance. In contrast, for RNOA, the coefficients in Panel A of Table 6 are not statistically significant.
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Acknowledgments
We acknowledge helpful comments from Bill Beaver, Peter Easton, Froystein Gjesdal, James Ohlson, Stephen Penman, two anonymous reviewers, participants at the 2006 Review of Accounting Studies conference and the 2006 Journal of Accounting, Auditing and Finance conference, and seminar participants at Berkeley, Bonn, Humboldt (Berlin), Notre Dame and UCLA. We are particularly grateful to Christine Botosan, Dan Dhaliwal and Marlene Plumlee for giving us access to their cost-of-capital datasets. Carlos Corona, Ian Gow, Alexander Nezlobin and Richard Saouma provided valuable research assistance.
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An erratum to this article can be found at http://dx.doi.org/10.1007/s11142-007-9044-1
Appendices
Appendix A
Proof of Lemma 1
Direct substitution yields
Collecting coefficients for each of the variables \({(d_{1},\ldots, d_{t})}\) on the right-hand side of the above equation, the coefficient for d i is:
Thus,
By the definition of neutral accounting,
Therefore \({\sum^{t}_{i=1} d_{i} \geq \sum^{t}_{i=1} d^{\ast}_{i}}\) is equivalent to \({\sum^{t}_{i=1} RI^{0}_{i} \cdot \gamma^{i} \le 0.}\) □
Proof of Proposition 1
The expression for ROI at date T is given in (1). Therefore \({ROI_{T}(\vec{\lambda})\ge r}\) is equivalent to:
where \({RI^{o}_{t} \equiv c^{o}_{t} - d_{t} \cdot b^{o} - r \cdot b^{o}(1-\sum^{t-1}_{i=1}d_{j})}\) denotes the residual income of the representative project \({\mathcal{P}=(b^{o}, c^{o}_{1}, \ldots, c^{o}_{T})}\). Lemma 1 shows that for any conservative depreciation schedule \({(d_{1}, \ldots, d_{T}):}\)
for all \({1 \le t \le T-1}\). The claim therefore amounts to showing that for any T−1 tuple \({(RI^{o}_{1}, \ldots , RI^{o}_{T-1})}\) satisfying (12), inequality (11) will be met if \({\lambda_{t} \le r}\). Since \({\Sigma^{T}_{i=1} RI^{o}_{i} \cdot \gamma^{i} = 0}\), inequality (11) can equivalently be written as:
The inequalities in (12) can be represented in matrix form as:
where
and \({\vec{RI}^{0}=(RI^{0}_{1}, \ldots ,RI^{0}_{T-1})}\). By Farkas Lemma (see Rockafellar 1970), (13) holds for any vector satisfying (14) if and only if there exists a non-negative row-vector \({v' = (v_1, \ldots, v_{T-1})}\) such that:
Since \({\Upgamma}\) is a diagonal matrix, the system of equations in (15) can be solved explicitly, yielding:
It follows that v t ≥ 0 if and only if \({\gamma^{-1} \ge (1 + \lambda_t)}\), or equivalently, \({ r \ge \lambda_t}\).
If the annual growth rates all exceed r, the claim is that inequality (13) reverses. The same line of arguments as before applies with the vector w′ ≥ 0, required by Farkas Lemma, given by:
Finally, for liberal accounting, the vector of residual income numbers satisfies:
Therefore the inequalities are “flipped,” such that (13) holds provided λ t ≥ r and the opposite is true for λ t ≤ r. □
Proof of Proposition 2
We show that:
provided that \({\sum^{t}_{i=1} u_{i} \ge 0}\) and λ t ≤ r for \({1 \le t \le T-1}\). It will be convenient to denote \({S_{t} \equiv \sum^{t}_{i=1} u_{i}}\). Referring back to the definition of ROI T in (1), the inequality in (16) is equivalent to:
where, by definition, S 0 = 0. We first note that:
because S T-1 ≥ 0, \({\lambda_{1} \le r}\) and \({ ROI_{T}(\vec{\lambda}, \vec{d}) \ge r}\). The latter claim is implied by Proposition 1, since the accounting is conservative and \({\lambda_{t} \le r}\) for all \({1 \le t \le T-1}\). Turning next to S T-2, the same arguments apply since:
Proceeding inductively, we conclude that for any \({1 \le t \le T-2}\):
provided \({S_{t} \ge 0, \ \lambda_{t} \le r}\) and \({ ROI_{T}(\vec{\lambda}, \vec{\delta}) \ge r}\); thus, (17) holds, as was to be shown. Finally, when growth is aggressive, i.e., \({\lambda_{t} \ge r}\), note that all inequalities are reversed since by Proposition 1 \({ROI_{T}(\vec{\lambda}, \vec{d}) \le r}\) whenever the accounting is conservative and \({\lambda_{t} \ge r}\). □
Proof of Proposition 3
To demonstrate that \({ ROI_{T}(\vec{\lambda})}\) is monotone decreasing in each λ t , we first establish the following technical result.
Claim
The function
is monotone decreasing in λ t provided: \({(i) \ \omega_{i+1}\ge \omega_i}\) and
for all 0 ≤ i ≤ T−2.
Proof of Claim
The numerator of the derivative of \({f (\vec \lambda)}\) with respect to λ t is given by:
Therefore \({\frac{\partial}{\partial \lambda_t} f(\vec \lambda) \le 0}\) whenever conditions (i) and (ii) are met.
To apply the above Claim, we recall that \({Inc_t^{o}= c_t^{o} -d_{t}\cdot b^{o}}\) and set:
Recalling that \({BV^{o}_t= (1- \sum^{t-1}_{i=1} d_{i})\cdot b^{o}}\), we also set:
Straightforward differentiation shows that the functions \({a_t (\vec{\lambda})}\) in (18) satisfy the elasticity conditions in part (ii) of the Claim. Finally, by neo-conservatism, RI 0 t is increasing in t. It follows that
since \({BV^0_{t-1} \ge BV^0_t}\). We conclude that
implying that \({\omega_0 \le \omega_1 \le \cdots \le \omega_{T-1}}\), as required by condition (i) in the Claim. □
Proof of Proposition 4
We first show that
is independent of the depreciation schedule \({(d_1,\ldots,d_T)}\) , where
and
Pulling out the factor (1 + λ)T, we observe that:
where \({RI^{o}_{t}(\lambda) \equiv Inc^{o}_{t} -\lambda \cdot BV^{o}_{t-1}}\). Since the residual income numbers \({RI^{o}_{t}(\lambda)}\) have the same present value as the underlying cash flows, the right hand side of (19) is equal to:
which obviously is independent of \({(d_1,\ldots,d_T)}\). If one chooses the depreciation schedule \({(d_1^{\ast},\ldots,d_T^{\ast})}\), which is neutral for \({\mathcal{P}}\), then by definition:
and
Using the above observation that \({RI_T^{\lambda}}\) is invariant to the depreciation schedule, we conclude that for any \({(d_1,\ldots,d_T)}:\)
or equivalently:
Proof of Lemma 2
Differentiating the function h(s), we obtain:
The monotonicity of h(·) in (21) follows from Bernoulli’s inequality. To establish convexity, first note that as \({s \rightarrow 0, (22) \rightarrow \frac{T^{2}-1}{6T}> 0.}\) Assume henceforth that s ≠ 0. We can ignore the positive \({T \cdot(1+s)^{T-2}}\) expression in front of (22). Now, for s ≠ 0, the denominator of (22) has the same sign as s. The numerator equals (1−T) < 0 as s → −1, and its value as well as its derivative equal 0 at s → 0. Further, its second derivative is given by the expression \({T(T-1)(T+1)s(1+s)^{T-2}}\), which has the same sign as s. Combining these facts, the numerator of (22) is monotone increasing and has an inflection point at s = 0, i.e., it has the same sign as s everywhere, thereby proving that (22) > 0 for all s. To prove that the ratio of h′(·) to h′′(·) increases in s, we use (21) and (22) to obtain the simplified ratio:
Letting z = (1 + s) > 0, (23) can be re-expressed as:
The key to the proof is to recognize that (z−1)3 is a factor of both the numerator and denominator of (24). Dividing through by this term, (24) can then be reduced to the following ratio of polynomials with positive coefficients:
We ignore the constant and differentiate (26) with respect to z. The resulting numerator, which we must show is positive, is the following polynomial of order (3T−4):
For \({1 \le i \le (3T-4)}\) , the coefficient of z i in (27) can then be simplified as follows:
Range of i | Coefficient of i |
---|---|
i ≤ (T−1) | \({\frac{1}{60}\cdot (1+i)\cdot (2+i) \cdot (3+i)\cdot [i^{2}(T+3)+i(7-11T)+20T(T-1)]}\) |
i = T | \({\frac{1}{60}\cdot T\cdot(T+1)\cdot(T-1)\cdot[T^{3}+18T^2+71T-162]}\) |
(T + 1) ≤ i ≤ (2T−3) | \({\frac{1}{60}\cdot\left({\begin{array}{l}-84i-190i^{2}-150i^ {3}-50i^{4}-6i^{5}+246t +784iT+760i^{2}T\cr +270i^3T+20i^4T-4i^5t-665T^2-1005iT^2-300i^2T^2 \cr +100i^3T^2+40i^4T^2+215T^3-335iT^3-540i^2T^3-150i^3T^3 \cr +485T^4+785iT^4+260i^2T^4-341T^5-205iT^5+60T^6 \end{array}}\right)}\) |
i ≥ (2T−2) | \({\begin{array}{l}\frac{1}{60}\cdot(T+1)\cdot(3T-i)\cdot[3T-1-i]\cdot[3T-2-i]\cr \quad\cdot[3T-3-i]\cdot[3i+7-4T]\end{array}}\) |
It can be verified that each of these coefficients is positive for any suitable values of T and i (details are available on request). As the polynomial in (27) is defined over the positive real line, we thus obtain the desired result that h′(·) is (strictly) log-concave everywhere. □
Proof of Proposition 5
Direct substitution yields:
The monotonicity of \({ROI_{T}(\lambda, \delta)}\) in λ follows from Proposition 3 and the observation that geometric depreciation results in neo-conservative accounting when cash flows are uniform and δ > −r. To prove convexity in λ, we let p = −δ and express (28) in the following form:
Differentiating (29) twice with respect to λ, we find that:
where \({Q(\lambda,p) = -h''(\lambda)(\lambda-p)[h(\lambda)-h(p)]-2h'(\lambda) \cdot [h(\lambda)-h(p)-h'(\lambda)(\lambda-p)]}\). We will demonstrate that for any \({\lambda \ne p,[h(\lambda)-h(p)] \cdot Q(\lambda,p) > 0}\). Since h(·) is an increasing function, (30) then immediately yields the desired results for conservative accounting, i.e., h(r) > h(p). Conversely, for liberal accounting ROI T (·, p) is concave in λ since (30) is negative when h(r) < h(p).
Fix some λ > −1 and consider the behavior of Q(·) in p. Note that Q(λ,λ) = 0 and Q p (λ,λ) = 0. In addition, we have:
For p < λ, \({\frac{h'(\lambda)}{h''(\lambda)} > \frac{h'(p)}{h''(p)}}\) by the log-concavity of h′(·), implying that Q pp (·) > 0. In turn, this implies that Q p (·) < 0 for p < λ and therefore that Q(·) > 0 for p < λ. We thus have \({[h(\lambda)-h(p)] \cdot Q(\lambda,p) > 0}.\)
For \({p > \lambda}\), a similar analysis of (31) using the log-concavity of h′(·) yields Q pp (·) < 0. This implies that Q p (·) < 0 for p > λ and thus Q(·) < 0 for p > λ. Again, we get [h(λ)−h(p)]·Q(λ,p) > 0, thereby completing the proof of the first claim.
To prove decreasing differences in λ and δ, we find it convenient to let p = −δ and to rewrite (28) as:
We show that the cross-partial of (32) in λ and p is positive when the accounting is conservative (i.e., p < r). Simplifying the cross-partial and ignoring its (positive) denominator, we find that the sign of \({\frac{\partial^2}{\partial \lambda \partial p} \left(ROI_{T}(\lambda, p)\right)}\) is given by the sign of:
We must show that F(λ,r,p) > 0 for p < r. Note that if p < r < λ, then, by the monotonicity and convexity of the h(·) function, (33) immediately yields F(·) > 0. Accordingly, we restrict attention to values of λ < r. Next, note that F(·) is symmetric in p and λ. With no loss of generality, we can thus assume that p < λ < r. Since h(·) is an increasing function, this implies that \({0 < [h(r)-h(\lambda)] < [h(r)-h(p)]}\), or:
where \({G(\lambda,p) = h'(\lambda) \cdot [h(\lambda)-h(p)-h'(p)(\lambda-p)] + h'(p) \cdot [h(\lambda)-h(p)-h'(\lambda)(\lambda-p)]}\). It is thus sufficient for us to demonstrate that G(·)≥0 for all values of λ > p. To do so, fix λ > −1 and consider the behavior of G(·) in p. First, note that \({G(\lambda,-1) = h(\lambda)h'(\lambda) > 0}\) and G(λ,λ) = 0. Moreover, \({G_p(\lambda,\lambda) = G_{pp}(\lambda,\lambda) = 0}\), while \({G_{ppp}(\lambda,\lambda)=[h'(\lambda)h'''(\lambda)-3h''(\lambda)^2] < 0}\), by the log-concavity of h′(·). Together, these facts imply that G(·) is positive at small values of p and is tangent to the origin line from above as p → λ. Finally, to verify that G(·) does not cut the origin line at any point prior to p = λ, we show that it cannot have a local maximum in this region. Suppose not, i.e., assume there exists p * < λ such that G p (λ,p *) = 0 and \({G_{pp}(\lambda,p^{\ast})\le 0}\). But, \({G_p(\lambda,p^{\ast})=0}\) implies:
In turn, (35) indicates that:
where the final inequality in (36) follows from p * < λ, the convexity of h(·), and the log-concavity of h′(·). This contradicts the supposition that p * is a local maximum, thus verifying that G(·) > 0 for all λ > p. □
Proof of Corollary 3
To establish the limit results (i)–(iii), we note that the limit result for λ → −1 is obvious. The result for λ → 0 follows from repeated applications of l’Hospital’s rule, as shown below:
The limit result as λ → ∞ follows from applying l’Hospital’s rule once more to the final expression above.
Proof of Proposition 6
If a β-fraction of new investments is expensed, steady state depreciation is given by:
The starting book value is simply scaled by (1−β), while cash flows and the specification of the internal rate of return (r) are unaltered. Income in the numerator of ROI T is therefore given by:
while book value in the denominator becomes:
Simplification of the resulting ratio then yields ROI T (λ,0,β):
The claim regarding the negative cross-partial derivative of ROI T (λ,0,β) follows immediately upon recalling that ROI T (λ,0) is everywhere decreasing in λ because setting δ = 0 corresponds to conservative accounting.
Appendix B
2.1 Alternative methods for calculating the cost of capital
2.1.1 Method 1: Target Price Method (r DIV )
The target price method, introduced in Botosan and Plumlee (2002), employs a short-horizon form where the infinite series of future cash flows is truncated at the end of year five by inserting a forecasted terminal value. This yields the equation below. The primary assumption underlying this method is that analysts’ forecasts of dividends per share during the forecast horizon and stock price at the end of the forecast horizon capture the market’s expectation of those values.
where:
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P0 = price at time t = 0.
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P5 = price at time t = 5.
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r DIV = estimated cost of equity capital.
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dps t = dividends per share.
Dividend forecasts for the current fiscal year (t = 1), the following fiscal year (t = 2), and the long run (t = 5), as well as maximum and minimum long-run target price estimates are collected from forecasts published by Value Line during the third quarter of the calendar year. Since Value Line does not provide dividend forecasts for years t = 3 and t = 4, we interpolate between the year t = 2 and t = 5 dividend forecasts using an implied straight-line rate of growth in dividends from year t = 2 to year t = 5.
Our forecast of terminal value (P 5) is the 25th percentile of Value Line’s forecasted long-run price range, although our conclusions are robust to the use of the 50th percentile or the minimum value. We use the 25th percentile to adjust for an apparent optimistic bias in analysts’ forecasts of target price. Current stock price (P 0) equals the stock price reported on CRSP on the Value Line publication date or closest date thereafter within 3 days of publication.
2.1.2 Method 2: Industry Method (r GLS )
The industry method, introduced by Gebhardt et al. (2001), employs a residual income valuation model derived from a 12-year forecast horizon. The following model results:
where
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\({ROE_t = \frac{eps_t}{b_{t-1}}}\) is the forecasted return on equity for period t.
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eps t = forecasted earnings per share in year t,
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b t = book value per share in year t,
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r GLS = estimated cost of equity capital,
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\({\gamma_{GLS} \equiv \frac{1}{1+ r_{GLS}}}\).
2.1.3 Method 3: PEG Ratio Method (r PEG )
The PEG method, introduced by Easton (2004), proceeds as follows:
Our method is similar, but we use long-run earnings forecasts (eps 5 and eps 4) in place of eps 2 and eps 1 (consistent with Botosan and Plumlee 2005). Accordingly, the empirical specification of the equation we employ to estimate r PEG is given by:
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Rajan, M.V., Reichelstein, S. & Soliman, M.T. Conservatism, growth, and return on investment. Rev Acc Stud 12, 325–370 (2007). https://doi.org/10.1007/s11142-007-9035-2
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DOI: https://doi.org/10.1007/s11142-007-9035-2