Abstract
This study extends the accounting-based valuation framework of Ohlson (Contemp Acc Res 11(2):661–687, 1995) and Feltham and Ohlson (Acc Rev 74(2):165–183, 1999) to incorporate dynamic expectations about the level of systematic risk in the economy. Our model explains recent empirical findings documenting a strong negative association between changes in economy-wide risk and future stock returns. Importantly, the model also generates costs of capital that are solely a linear function of accounting variables and other firm fundamentals, including the book-to-market ratio, the earnings-to-price ratio, the forward earnings-to-price ratio, size and the dividend yield. This result provides a theoretical rationale for the inclusion of these popular variables in cost of capital (expected return) computations by the accounting and finance literatures and obviates the need to estimate costs of capital from unobservable (future) covariances. The model also generates an accounting return decomposition in the spirit of Vuolteenaho (J Finance 57(1):233–264, 2002). Empirically, we find that costs of capital generated by our model are significantly associated with future returns both in and out of sample in contrast to standard benchmark models. We further obtain significantly lower valuation errors in out-of-sample tests than traditional models that ignore dynamic risk expectations.
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Notes
As we show further below, the dividend yield can be eliminated using the clean surplus relation in which case the cost of capital can be expressed solely (in addition to size) as a linear function of accounting numbers, namely, the past book-to-market ratio, the current book-to-market ratio, the earnings-price ratio, and the forward earnings-price ratio.
See Ohlson (2009) and the citations therein.
See their Corollary 3.
To the best of our knowledge, Morel (2003) is the first paper to decry this disconnect and attempt to deal with it.
The latter assumption is for simplicity. Relaxing this condition would increase the number of variables in the stock price equation by one.
Because our analysis is in discrete time, this specific form of discount factor may yield negative values. We assume that does not occur
This result obtains by assuming that the market portfolio has stochastic risk. This is a straightforward extension of the basic derivations in Cochrane (2001), Chapter 9.
We have also solved for a model where risk follows a mean-reverting process. The implications of our results do not change even when risk is assumed to mean-revert.
The result that λ1 is positive presumes a positive correlation (ρ) between shocks to abnormal earnings (\(\epsilon_{t+1}\)) and shocks to the stochastic discount factor (e t+1). On average it is unlikely to be otherwise as long as growth in the economy and growth in firm level abnormal earnings are positively correlated. To complete the argument note that the discount factor represents the marginal rate of consumption in the economy or growth in the economy—see “Appendix 1”. Therefore shocks to the discount rate factor are driven by shocks to aggregate consumption or shocks to aggregate growth, represented by e t+1 which, in turn, should be positively related to shocks to (abnormal) earnings \(\epsilon_{t+1}\).
Note that λ1 is the firm level driver of expected returns being a function of the persistence of abnormal earnings, the volatility of abnormal earnings, and the correlation between (shocks to) abnormal earnings and (shocks to) economy-wide systematic risk in the economy.
The restriction on earnings growth does not affect any of our results, if anything our results are stronger when we remove this restriction.
Particularly, we measure next period expected earning by multiplying 1 year ahead concensus IBES earnings by w d and 2 year ahead concensus IBES earnings by 1 − w d where w d is the difference between the firms ficscal year end date and the current forecast date divided by 365.
We assume that long-run abnormal earnings are cross-sectionally constant, consistent with the notion that, in the long-run, a firm will grow to the point where it resembles a cross-section of firms.
The results in this and the following tables are not sensitive to the size of the estimation window.
Letting \(Z_{t}=(R_{f}-1)\frac{VIX_{t}}{S_{t}}-\frac{\Updelta VIX_{t}}{S_{t}},\) we also include Z t-1 in the regression.
The firm-level \(\hat{\lambda}_{1},\) estimated market beta, and estimated FF factor betas are updated annually each April.
Since \(\hat{\lambda}_{1}\) is already an estimated coefficient, we force a coefficient of one for \(\frac{\hat{\lambda}_{1}VIX_{t}}{B_{t}}\) when estimating Eq. (18).
Industries are based on the Fama–French 48 industry classifications downloaded from Ken French’s website.
Specifically, the two RIM models used assume a functional form of \(S_{t}=B_{t}+\sum_{i=1}^{T}E_{t}[\frac{x_{t+i}^{a}}{(1+r)^{i}}]+E_{t}[\frac{x_{t+i}^{a}(1+g)}{(1+r)^{5}(r-g)}]\), where B t is book value, x a t+i is abnormal earnings at time t + i and g is growth in abnormal earnings. It is assumed that T = t + 5 and a long-term growth rate of 0. Various other assumptions of long-term growth tended to yield higher valuation errors than the assumption of zero growth.
The effects of winsorizing the data and constraining the absolute pricing error to 1 reduces the performance of our model relative to the benchmarks. If we do not apply these filters, our model does even better than what is presented in the tables relative to the benchmark models.
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Acknowledgements
We owe a debt of gratitude to the anonymous reviewers of this Journal and Jim Ohlson (the editor) for their insightful comments and guidance. We also wish to thank Judson Caskey, Sandra Chamberlain, Mark Huson, Yu Hou, Alastair Lawrence, Miguel Minutti-Meza and Dan Segal for their helpful comments. Finally, we acknowledge the remarks by workshop participants at Singapore Management University and Cyprus University of Technology, and by conference participants at the AAA, CAAA and FARS 2012 conferences.
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Appendices
Appendix 1
1.1 Derivation of the discount factor
The stochastic discount factor m t,t+1 is defined as the marginal rate substitution of aggregate consumption between two periods (see Cochrane 2001):
where \(U(\cdot) \) is a representative agent’s utility function, and C t is aggregate consumption. Assuming a standard power utility economy with a risk aversion parameter α, then
If consumption grows at the rate g t+1, then next period consumption is \(C_{t+1}=C_{t}\exp (g_{t+1})\) so that:
where a and b > 0 are constants. This result accords both with intuition and general linear asset pricing models. Firms whose (abnormal) earnings are positively correlated with aggregate consumption are discounted more because of risk aversion—note the negative sign in Eq. (24)—consistent with the implications of the consumption CAPM.
The expectation of m t,t+1 must be the gross risk-free discount rate, E t [m t,t+1] = R −1 f , which implies in turn that
Assuming that growth in aggregate consumption takes the dynamics g t+1 = g + σ g,t e t+1 and that σ g,t+1 = σ g,t + ξ t+1 (where e t+1 and ξ t+1 are mean zero random variables as in the text), then
Calling bR f σ g,t ≡ σ m,t yields the same form of the dynamic discount factor used in this study:
This discount factor readily relates to the CAPM. Assume that consumption can be proxied by the wealth in the market portfolio, then Eq. (24) can be replaced with the discount factor that generates the CAPM:
where r m,t+1 is the return on the market portfolio.
Appendix 2
2.1 Proof of Proposition 1
The underlying dynamics are given by:
All error terms are assumed to be i.i.d and are orthogonal to one another except for \(\epsilon_{t+1}\) and e t+1, which have a correlation coefficient of ρ. The expectation operator \(E_{t}[\cdot ]\) represents a conditional expectation given information at time t.
From Eq. (1) in the text, the price of the equity is given by:
Let z t+1 = x a t+1 m t,t+1, then
By the law of iterated expectations:
Again, using the law of iterated expectations, we can write:
We solve the expectation by moving from right to left:
Similarly,
Finally,
Thus,
The pattern emerges, and we see that
Now evaluating the summation yields:
Thus the form of the stock price is:
which is Eq. (6) of Proposition 1.
To prove Eq. (7) of Proposition 1, substitute out "other information" as follows:
This implies that
Substituting the latter into the price equation, we can now rewrite price in terms of accounting data and expected next period abnormal earnings. Specifically,
Noting that
and substituting, yields Eq. (7):
\(\square\)
2.2 Proof of proposition 2
Therefore,
Now subtracting R f S t from the latter equation gives:
and
Collecting like-terms yields:
So,
Thus,
The gross stock return is then given by:
Taking conditional expectations provides the expected stock return:
\(\square\)
2.3 Proof of proposition 3
From the preceding proof, we have
Substitute the latter into the value equation yields:
To prove Eq. (11), we use (7) of Proposition 1. That is, we substitute "other information," v t , with next period expected earnings as outlined in the proof of Proposition 1. Combining this with the results in Proposition 2 yields the (net) return dynamics:
Taking conditional expectations of both sides yields the desired result.
\(\square\)
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Lyle, M.R., Callen, J.L. & Elliott, R.J. Dynamic risk, accounting-based valuation and firm fundamentals. Rev Account Stud 18, 899–929 (2013). https://doi.org/10.1007/s11142-013-9227-x
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DOI: https://doi.org/10.1007/s11142-013-9227-x