Modelling Dependence with Copulas - IFOR
Modelling Dependence with Copulas - IFOR
Modelling Dependence with Copulas - IFOR
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9 <strong>Modelling</strong> Extremal Events in Practice<br />
9.1 Pricing Risky Insurance Contracts<br />
Consider a portfolio consisting of n risks X 1 ,... ,X n which are positive. Let the<br />
risks represent potential losses in dependent lines of business for an insurance company.<br />
Suppose that losses not greater than k 1 ,... ,k n can be accepted, and that the<br />
insurance company wants to buy protection against the situation where l or more<br />
of the losses simultaneously exceed their respective thresholds k 1 ,... ,k n . Suppose<br />
that a reinsurance company offers to sell a contract which makes a payout only in<br />
thecasethatatleastl of the n risks exceeds their thresholds. To begin <strong>with</strong> we will<br />
look at the probability that a payout is made. Later we will look at the expected<br />
size of the payout under the assumption that losses which exceed their thresholds<br />
are paid in full.<br />
Assume historical data are available allowing estimation of<br />
Let<br />
• marginal distributions;<br />
• pairwise rank correlations.<br />
N = | { i ∈{1,...,n}|X i >k i<br />
}<br />
|<br />
be the number of losses exceeding their thresholds and let<br />
L l = 1 {N≥l}<br />
n ∑<br />
i=1<br />
(<br />
Xi 1 {Xi>k i})<br />
be the loss to the reinsurer.<br />
Suppose that the contract the insurance company is interested in is the one<br />
for which the losses are paid in full when all losses exceed their thresholds. If the<br />
insurance company holds this contract it has full protection against simultaneous<br />
big losses in all lines of business no matter how big the total loss is. The probability<br />
of payout is then given by<br />
P[N = n] =H(k 1 ,... ,k n ).<br />
Unfortunately a good estimation of the joint distribution, H, is not realistic due to<br />
lack of data and theoretical difficulties. However, data from the previous year(s) enable<br />
estimation of the Kendall’s tau rank correlation matrix via the sample version.<br />
Furthermore, estimation of univariate marginal distributions is well understood.<br />
Hence we can assume that rank correlations and margins are given. Since<br />
H(x 1 ,... ,x n )=Ĉ(F 1(x 1 ),... ,F n (x n )),<br />
the payout probability can not be calculated <strong>with</strong>out choosing a suitable copula<br />
representing the dependence structure among the n risks. The standard approach<br />
might be to choose a Gaussian copula, given by<br />
Cρ Ga<br />
l<br />
(u) =Φ n ρ l<br />
(Φ −1 (u 1 ),... ,Φ −1 (u n )),<br />
where Φ n ρ l<br />
denotes the joint distribution function of the n-variate standard normal<br />
distribution function <strong>with</strong> linear correlation matrix ρ l and Φ −1 denotes the inverse<br />
of the distribution function of the univariate standard normal distribution. To<br />
parametrizise the Gaussian copula from the estimated Kendall’s tau rank correlation<br />
matrix the relation<br />
ρ l = sin(πτ/2)<br />
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