Abstract
We establish new conditions under which a constrained (no short-selling) time-consistent equilibrium strategy, starting at a certain time, will beat the unconstrained counterpart, as measured by the magnitude of their corresponding equilibrium mean–variance value functions. We further show that the pure strategy of solely investing in a risk-free bond can sometimes simultaneously dominate both constrained and unconstrained equilibrium strategies. With numerical experiments, we also illustrate that the constrained strategy can dominate the unconstrained one for most of the commencement dates (even more than 90%) of a prescribed planning horizon. Under a precommitment approach, the value function of an investor increases with the size of the admissible sets of strategies. However, this may fail to be true under the game-theoretic paradigm, as the constraint of time-consistency itself affects the value function differently when short-selling is and is not prohibited.
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Notes
It is reasonable to assume an increasing function of \(\gamma_{t}\) since people usually look for a more stable income as they get older, so they become more risk-averse, relative to their current wealth, as time evolves.
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Acknowledgements
We are very grateful to various participants for their valuable discussions and comments after the talks based on the present work. We thank our colleague John Wright for his suggestions on enriching the presentation of our paper. We express our sincere gratitude to the editors and anonymous referees for their very useful suggestions and inspiring comments which much enhanced our article. The first author acknowledges the financial support from the National Science Foundation under grant DMS-1612880, and the Research Grant Council of Hong Kong Special Administrative Region under grant GRF 11303316. The second author acknowledges the financial support from ERC (279582) and SFI (16/IA/4443,16/SPP/3347), and the present work constitutes a part of his work for his postgraduate dissertation. The third author acknowledges the financial support from HKGRF-14300717 with the project title: New Kinds of Forward–Backward Stochastic Systems with Applications, HKSAR-GRF-14301015 with title: Advance in Mean Field Theory, Direct Grant for Research 2014/15 with project code: 4053141 offered by CUHK. He also thanks Columbia University for the kind invitation to be a visiting faculty member in the Department of Statistics during his sabbatical leave. The third author also recalls the unforgettable moments and the happiness shared with his beloved father during the drafting of the present article at their home. Although he just lost his father with the deepest sadness at the final stage of the review of this work, his father will never leave the heart of Phillip Yam; and he used this work in memory of his father’s brave battle against liver cancer.
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Appendix: Technical proofs in Sect. 4
Appendix: Technical proofs in Sect. 4
1.1 A.1 Proof of Theorem 4.1
Recall (1.7) and (1.9). Then (4.1) implies \(c^{(U)}_{T}=c^{(C)}_{T}<1\). Because we have \(G(x)=x\) when \(x\in(0,1)\) (see Theorem 1.6), we get for any \(t\) with \(c^{(C)}_{t} \in(0,1)\) that \(c^{(C)}_{t}=G(\frac{\alpha_{t}}{\sigma^{2}_{t}} d^{(C)}_{t})=\frac{\alpha_{t}}{\sigma^{2}_{t}} d^{(C)}_{t}\) by (1.9). Thus both \(c^{(C)}_{\cdot}\) and \(c^{(U)}_{\cdot}\) satisfy the same form of integral equations (see (1.7) and (1.9)) over \([t,T]\). Therefore, \(c^{(U)}_{t}=c^{(C)}_{t} \in(0,1)\) for any \(t>\sup\{t< T: c^{(C)}_{t} \notin(0,1) \}\). By Lemmas 3.1 (i) and 3.5 (i), (4.2) implies that both \(c^{(U)}\) and \(c^{(C)}\) are increasing in \(t\) whenever \(c^{(U)}_{t}=c^{(C)}_{t}>0\). Define
We consider two separate cases:
(i) If \(\tau^{*}_{0}=-\infty\), then \(c^{(U)}_{t}=c^{(C)}_{t} \in(0,1)\) for all \(t\leq T\) and it is clear that \(V^{(U)}(t,x)= V^{(C)}(t,x)\) for all \(t \leq T\) and \(x>0\).
(ii) If \(\tau^{*}_{0}>-\infty\), we have \(c^{(U)}_{t}=c^{(C)}_{t} \in(0,1)\) for all \(t \in(\tau^{*}_{0},T)\) and \(c^{(U)}_{t} \leq c^{(C)}_{t}=0\) for all \(t <\tau^{*}_{0}\) because of Lemmas 3.1 (i) and 3.5 (i). Therefore, we obtain \(V^{(U)}(t,x)= V^{(C)}(t,x)\) for all \(t \in[\tau^{*}_{0},T]\) and \(x>0\). Recall that the equilibrium value function in terms of the investment-to-wealth ratio \(c\) is
Differentiating the product \(e^{-\int^{T}_{t} r_{s} ds} V(t,x)\) gives
We can then deduce that for any \(t < \tau^{*}_{0}\) and \(x>0\),
where the first equality follows because \(c^{(C)}_{t}=0\) for \(t <\tau^{*}_{0}\), \(c^{(C)}_{t}=c^{(U)}_{t}\) for \(t \in[\tau^{*}_{0},T]\) and \(c^{(U)}_{t}\) satisfies (1.7). Next we compute
for \(t<\tau^{*}_{0}\), where the second equality follows from (1.7), and the positivity from the fact that \(c^{(U)}_{t} \leq0\) for \(t<\tau^{*}_{0}\). Hence we have
for \(t<\tau^{*}_{0}\). Together with the result in (4.2), the inequality (A.2) thus becomes
Since \(V^{(U)}(\tau^{*}_{0},x)=V^{(C)}(\tau^{*}_{0},x)\), we have for \(t<\tau ^{*}_{0}\) and \(x>0\) that
and so the claim follows. □
1.2 A.2 Proof of Theorem 4.3
We only prove the constrained case and omit the unconstrained one as its argument is analogous. Using the differentiation in (A.1), we have for \(t \leq T\) and \(x>0\) that
where the first inequality follows from (4.3). On the other hand, (1.9) gives
whenever \(c^{(C)}_{t} \geq0\). Thus (A.3) now becomes
Hence
and our claim is justified for the constrained case. □
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Bensoussan, A., Wong, K.C. & Yam, S.C.P. A paradox in time-consistency in the mean–variance problem?. Finance Stoch 23, 173–207 (2019). https://doi.org/10.1007/s00780-018-00381-0
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DOI: https://doi.org/10.1007/s00780-018-00381-0
Keywords
- Time-consistency
- Mean–variance
- State-dependent risk-aversion
- Equilibrium strategy
- Short-selling prohibition