Abstract
The purpose of this paper is to analyze the gap risk of dynamic portfolio insurance strategies which generalize the “Constant Proportion Portfolio Insurance” (CPPI) method by allowing the multiple to vary. We illustrate our theoretical results for conditional CPPI strategies indexed on hedge funds. For this purpose, we provide accurate estimations of hedge funds returns by means of Johnson distributions. We introduce also an EGARCH type model with Johnson innovations to describe dynamics of risky logreturns. We use both VaR and Expected Shortfall as downside risk measures to control gap risk. We provide accurate upper bounds on the multiple in order to limit this gap risk. We illustrate our theoretical results on Credit Suisse Hedge Fund Index. The time period of the analysis lies between December 1994 and December 2013.
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Notes
For example, it is well known that portfolio managers cannot actually modify their portfolio weights in continuous time. Additionally, asset liquidity problems may occur, especially during stock markets crashes (see Longin 1997).
Since we consider small time intervals , we set \(r_{t_{k} }=0\).
Since we assume that the pdf of the random variables \(\epsilon \) is non negative, the probability of the event \(C_{t_{k-1}}=L_{t_{k-1}}\) is null.
For the proofs of the results that follow, see “Appendix”.
We choose the Multi-Strategy index since composed of several other types of hedge fund and so it’s the only index that can represent a maximum of hedge fund strategies.
Note that this condition is satisfied as soon as \(L_{t_{k-1}}>0.\)
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Appendix
Appendix
1.1 Proofs of Propositions 8 and 9
In what follows, the cushion at time \(t_{k-1}\) is strictly positive (\(C_{t_{k-1}}>0\)).
1.1.1 Case 1: \(C_{t_{k-1}}>L_{t_{k-1}}\) (Proposition 8)
The local quantile condition is the following:
which is equivalent to:
At time \(t_{k}\), we have two cases:
We assume that the multiple \(m_{t_{k-1}}\ \)is higher than 1 , (thus, it is non negative).
Then, we deduce:
1.1. If \(C_{t_{k-1}}>L_{t_{k-1}},\) then:
Note that we have:
Then, if the condition \(\frac{\frac{L_{t_{k-1}}}{C_{t_{k-1}}}-1}{m_{t_{k-1}} }+1>0\) is fulfilled, we have: \(R_{t_{k}}>\frac{\frac{L_{t_{k-1}}}{C_{t_{k-1}} }-1}{m_{t_{k-1}}}+1.\) Footnote 6
1.1.1. If we have \(\frac{\frac{L_{t_{k-1}}}{C_{t_{k-1}}}-1}{m_{t_{k-1}}}+1<0, \) then the condition \(R_{t_{k}}>\frac{\frac{L_{t_{k-1}}}{C_{t_{k-1}}} -1}{m_{t_{k-1}}}+1\) is satisfied and:
1.1.2. Examine the case \(C_{t_{k-1}}>0\), \(C_{t_{k-1}}>L_{t_{k-1}}\) and \(\frac{\frac{L_{t_{k-1}}}{C_{t_{k-1}}}-1}{m_{t_{k-1}}}+1>0.\)
We have:
which is equivalent to:
Denote by N the cdf of the standard Gaussian distribution (the cdf of \(\varepsilon _{t_{k}}\)). We have:
which is equivalent to:
and also equivalent to:
Recall that \(q_{(\epsilon ,T)}=N^{-1}\left[ \left( 1-(1-a)\right) ^{\frac{1}{T}}\right] .\)
Finally, we have:
(i) If \(\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] <1,\)
If \(\frac{L_{t_{k-1}}}{C_{t_{k-1}}}<\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] ,\) then \(m_{t_{k-1}}\)must satisfy the following constraint:
If \(\frac{L}{C_{t_{k-1}}}>\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] ,\) then the previous constraint must be satisfied but also involves more that \(m_{t_{k-1}}<1.\)
(ii) If \(\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] >1,\) then there is no constraint for \(m_{t_{k-1}}.\)
1.1.2 Case 1: \(0<C_{t_{k-1}}<L_{t_{k-1}}\) (Proposition 9)
As previously, the quantile condition is given by:
which is equivalent to:
At time \(t_{k}\), we have two cases:
We assume that the multiple \(m_{t_{k-1}}\ \)is non negative.
Therefore, we have:
Consequently, we get the equivalence between the two following conditions:
This is equivalent to:
Thus, the quantile condition is equivalent to:
And also to:
We obtain:
Finally, we have:
2-1) If \(\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] <1,\) there is no positive solution for \(m_{t_{k-1}}\)
2-2) If \(\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] >1,\) then:
If \(\frac{L_{t_{k-1}}}{C_{t_{k-1}}}<\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] ,\) then there is no constraint for \(m_{t_{k-1}}\)
If \(\frac{L_{t_{k-1}}}{C_{t_{k-1}}}>\exp \left[ h_{t_{k}}^{-1}\left( q_{_{(a,T})}^{\varepsilon }\right) \sigma _{t_{k}}+\mu _{t_{k}}\right] ,\) then \(m_{t_{k-1}}\)must satisfy the following constraint:
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Naguez, N. Dynamic portfolio insurance strategies: risk management under Johnson distributions. Ann Oper Res 262, 605–629 (2018). https://doi.org/10.1007/s10479-016-2121-8
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DOI: https://doi.org/10.1007/s10479-016-2121-8