Abstract
This paper investigates how welfare losses for facing high-order risk increases change when the risk environment of the decision maker is altered. To that aim, we define the nth-order utility premium as a measure of pain associated with facing the passage of one risk to a more severe one and we examine some of its properties. Changes in risk are expressed through the concept of stochastic dominance of order n. The paper investigates more particularly welfare changes of merging increases in risk, first ignoring background risks, then taking them into account. Merging increases in risk may be beneficial or not, depending on whether background risks are considered and how. The paper also provides conditions on individual preferences for superadditivity of the nth-order utility premium. The results confirm the importance and usefulness of two analytical concepts: mixed risk aversion and risk apportionment.
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Notes
See Eeckhoudt and Gollier (2013) for a review.
Note, however, that a well-known deficiency of the utility premium compared to the risk premium is its inadequacy for interpersonal comparisons. This is due to the fact that the utility premium is not unique under linear transformations of the utility function. To circumvent this difficulty, Crainich and Eeckhoudt (2008) introduced the monetary utility premium—the utility premium divided by the marginal utility. Li et al. (2014) and Huang and Stapleton (2015) have used the monetary utility premium to derive comparative risk aversion results. In this paper, we do not address interpersonal comparisons of loss of welfare.
See our equation (16) below.
We assume that the support of \({\tilde{\epsilon }}\) is defined such that \( x+\epsilon \) is in the domain of u.
We assume throughout this article that the utility function u is n-times differentiable. As usual, we assume that the derivative of order k (\( \forall k\ge 1\)), denoted \(u^{(k)}(x)\), has a constant sign in the domain of u: \(u^{(k)}(x)\ge 0\) or \(u^{(k)}(x)\le 0\) \(\forall x\).
We assume throughout this article that the support of any random variable \( {\tilde{z}}\) is defined such that \(x+z\) is in the domain of u.
The nth-order utility premium was already used by Eeckhoudt et al. (2009) as well as by Ebert et al. (2017) without being given a name. However, Harris Schlesinger referred to this utility premium as the “comparative utility premium” during a presentation of an earlier version of Ebert et al. (2017) at the 2013 EGRIE seminar in Paris.
We thank a referee for pointing out the link between the two properties.
Risk vulnerability means that risk aversion increases with the presence of an independent background risk (Gollier and Pratt 1996). Sufficient and necessary conditions on the utility function to have risk vulnerability are quite complex. A necessary condition for risk vulnerability is \(u^{(4)}\le 0 \).
Note, however, that if risk apportionment of order n holds, recent work by Menegatti (2015) shows that risk apportionment of order j will hold, for \( j=2,\ldots ,n-1\), under very general conditions on the utility function. We are thus brought back to the condition of Corollary 2, even when Ekern increases in risk of order n are considered, instead of stochastic dominance of order n.
The concept of edginess, i.e. \(u^{(5)}\ge 0\), was introduced by Lajeri-Chaherli (2004) to explain the effects of background risks on precautionary savings.
Indeed, it is easy to verify that \(w(x+Z;Y,X)\) and \(w(x;Y+Z,X+Z)\) both write as \(E[u(x+Z+Y)]-E[u(x+Z+X)]\).
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Acknowledgements
We would like to thank the participants of the CEAR/MRIC Behavioral Insurance Workshop 2016 held in Munich and of the 44th Seminar of the European Group of Risk and Insurance Economists held in London as well as two anonymous referees for valuable comments and discussions. We are also very grateful to Sebastian Ebert for his careful reading of successive versions of this paper. His appropriate comments have substantially improved the paper.
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Appendix
Appendix
Proof of Proposition 1
We have \(X_2 \preceq _{{n_2}-SD} Y_2\) and \(Y_1 \preceq _{2-SD} 0\). Applying Eeckhoudt et al. (2009), we know that \( E[u(x+Y_{2})]+E[u(x+X_{2}+Y_{1})]-E[u(x+X_{2})]-E[u(x+Y_{1}+Y_{2})]\le 0\) for all u such that \((-1)^{(1+k)}u^{(k)}\ge 0\) \(\forall k=1,\ldots ,n_2+2\).
Analogously, we have \(X_{1}\preceq _{{n_{1}}-SD}Y_{1}\) and \(Y_{2}\preceq _{2-SD}0\). Applying Eeckhoudt et al. (2009), we know that \( E[u(x+Y_{1})]+E[u(x+X_{1}+Y_{2})]-E[u(x+X_{1})]-E[u(x+Y_{1}+Y_{2})]\le 0\) for all u such that \((-1)^{(1+k)}u^{(k)}\ge 0\) \(\forall k=1,\ldots ,n_{1}+2\). However, from Eeckhoudt et al. (2009) we get \( E[u(x+Y_{1}+Y_{2})]+E[u(x+X_{1}+X_{2})]-E[u(x+X_{1}+Y_{2})]-E[u(x+Y_{1}+X_{2})]\le 0 \) for all u such that \((-1)^{(1+k)}u^{(k)}\ge 0\) \(\forall k=1,\ldots ,n_{1}+n_{2}\). Consequently, if u is such that \((-1)^{(1+k)}u^{(k)}\ge 0\) \(\forall k=1,\ldots ,n_{1}+n_{2}\), \(\forall n_{1}\ge 2\), \(\forall n_{2}\ge 2\) then the following inequality holds: \(\Bigl ( E[u(x+Y_{2})]+E[u(x+X_{2}+Y_{1})]-E[u(x+X_{2})]-E[u(x+Y_{1}+Y_{2})]\Bigr )+ \Bigl (E[u(x\!+Y_{1})]+E[u(x+X_{1}+Y_{2})]\!-E[u(x+X_{1})]-E[u(x+Y_{1}+Y_{2})] \Bigr )+\Bigl ( E[u(x+Y_{1}+Y_{2})]+E[u(x+X_{1}+X_{2})]\!-E[u(x+X_{1}+Y_{2})]-E[u(x+Y_{1}+X_{2})] \Bigr )\le 0\). It rewrites equivalently as \( E[u(x+Y_{1})]-E[u(x+X_{1})]+E[u(x+Y_{2})]-E[u(x+X_{2})]\le E[u(x+Y_{1}+Y_{2})]-E[u(x+X_{1}+X_{2})\) that is equivalent to \( w(x;Y_{1},X_{1})+w(x;Y_{2},X_{2})\le w(x;Y_{1}+Y_{2},X_{1}+X_{2})\) that ends the proof. \(\blacksquare \)
Proof of Corollary 1
Let us define \(Y=Y_{1}+Y_{2}.\) Assuming \(X_{1}\preceq _{n_{1}-SD}(Y_{1}+Y_{2}) \) and \(X_{2}\preceq _{n_{2}-SD}(Y_{1}+Y_{2})\), we want to prove that Proposition 1 implies Corollary 1. As \(Y_{1}\), \(Y_{2}\), \( X_{1}\), \(X_{2}\) are mutually independent, we have \(Y\perp X_{1}\), \(Y\perp X_{2}\). As \(Y_1 \preceq _{2-SD} 0\) and \(Y_2 \preceq _{2-SD} 0\), we have (using the convolution property) \(Y_1+Y_2 \preceq _{2-SD} 0\). Assumptions of Corollary 1 hold.
Equation (17) (i.e. the claim of Corollary 1) rewrites then \( w(x;Y_{1}+Y_{2},X_{1}+X_{2})\ge w(x;Y_{1}+Y_{2},X_{1})+w(x;Y_{1}+Y_{2},X_{2})\) that we label \((17^{\prime })\). Equation (16) (i.e. the claim of Proposition 1) writes as \( w(x;Y_{1}+Y_{2},X_{1}+X_{2})\ge w(x;Y_{1},X_{1})+w(x;Y_{2},X_{2})\).
We show (see proof below) that \(w(x;Y_{1},X_{1})\ge w(x;Y_{1}+Y_{2},X_{1})\) and \(w(x;Y_{2},X_{2})\ge w(x;Y_{1}+Y_{2},X_{2})\). Using this result we obtain Eq. (16) \(\Rightarrow \) Eq. (17\(^{\prime }\)).
To prove that \(w(x;Y_{1},X_{1})\ge w(x;Y_{1}+Y_{2},X_{1}),\) we use the definition of the nth-order utility premium. Then \(w(x;Y_{1},X_{1})\ge w(x;Y_{1}+Y_{2},X_{1})\) writes equivalently as \(E[u(x+Y_{1}+Y_{2})]\le E[u(x+Y_{1})]\) which is true for all u such that \(u^{\prime \prime }<0\) as \(Y_{1}\) and \(Y_{2}\) are zero-mean independent risks. The proof is the same for \(w(x;Y_{2},X_{2})\ge w(x;Y_{1}+Y_{2},X_{2})\). \(\blacksquare \)
Proof of Corollary 2
Using the definition of w, \(w(x+X_{2};Y,X)-w(x+Y_{2};Y,X)\ge 0\) rewrites equivalently as \(E[u(x+Y+X_{2})]-E[u(x+X+X_{2})]\ge E[u(x+Y+Y_{2})]-E[u(x+X+Y_{2})]\), that is equivalent to \( E[u(x+Y+X_{2})]+E[u(x+X+Y_{2})]\ge E[u(x+Y+Y_{2})]+E[u(x+X+X_{2})]\). Following Eeckhoudt et al. (2009), this last expression is equivalent to \( (-1)^{(1+k)}u^{(k)}\ge 0\) for \(k=1,\ldots ,n_{1}+n_{2}\). \(\blacksquare \)
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Courbage, C., Loubergé, H. & Rey, B. On the properties of high-order non-monetary measures for risks. Geneva Risk Insur Rev 43, 77–94 (2018). https://doi.org/10.1057/s10713-018-0029-8
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DOI: https://doi.org/10.1057/s10713-018-0029-8
Keywords
- Mixed risk aversion
- Risk apportionment
- Merging increases in risk
- Superadditivity
- nth-order utility premium