Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
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tel-00703797, version 2 - 7 Jun 2012<br />
function is given by<br />
P (Y = k) =<br />
π if k = 0,<br />
1.5. Testing asymmetry of information<br />
(1 − π) λk<br />
k! e−λ otherwise.<br />
Note that Y is a mixture of a Bernoulli distribution B(π) with a Poisson distribution P(λ).<br />
The mean of the zero-inflated Poisson distribution is (1 − π)λ. Using the GLM framework<br />
and the ca<strong>non</strong>ical link functions, a zero-inflated GLM Poisson mo<strong>de</strong>l is <strong>de</strong>fined as<br />
E(Y/ xi) =<br />
1<br />
1 + e x1 T e<br />
i γ x2 i<br />
where the covariate vectors x 1 i , x2 i are parts of the vector xi. Now there are two (vector)<br />
coefficients to estimate β and γ. The GLM is implemented in R base by the glm function.<br />
For the zero-inflated mo<strong>de</strong>l, we need to use the pscl package, cf. Jackman (2011).<br />
Still studying the FC agent dataset, we fit three distributions on the claim number: Poisson,<br />
zero-inflated Poisson and Negative binomial distributions. As shown in Table 1.19 in<br />
Appendix 1.8.2, the three mo<strong>de</strong>ls are similar in terms of log-likelihood or AIC. But, differences<br />
appear at the predictions.<br />
Despite being equivalent for first probabilities P (X = 0, 1, 2), classic and zero-inflated<br />
Poisson distributions <strong>de</strong>crease too sharply compared to the observed number of claims. The<br />
negative Binomial distribution (fourth line) is far better. In Appendix 1.8.2, we give the<br />
regression summary for zero-inflated negative binomial distribution on the FC agent subset.<br />
We obtain the same conclusion for other FC subsets.<br />
Claim number 0 1 2 3 4 5 6<br />
Observed 43687 5308 667 94 17 2 2<br />
Poisson 43337.9 5896.0 500.9 39.8 3.7 0.417 0.054<br />
zeroinfl. Poisson 43677.6 5267.7 745.0 80.2 7.5 0.665 0.058<br />
zeroinfl. NB 43704.6 5252.6 704.7 98.8 14.9 2.457 0.442<br />
Table 1.15: Claim number prediction for Full Comp. agent subset<br />
Testing adverse selection<br />
Now that we have mo<strong>de</strong>lled the claim frequency, we turn to the mo<strong>de</strong>lling of the <strong>de</strong>ductible<br />
choice as <strong><strong>de</strong>s</strong>cribed in the previous section: an or<strong>de</strong>red logistic mo<strong>de</strong>l. We test for evi<strong>de</strong>nce of<br />
adverse selection on three datasets: agent, broker and direct with Full. Comp. products. Let<br />
us note that we cannot test adverse selection on TPL covers, since there is no <strong>de</strong>ductible for this<br />
cover. As reported in Subsection 1.5.1, adverse selection testing is done by a fit of a GLM to<br />
explain the <strong>de</strong>ductible choice Zi. In addition to the exogeneous variables Xi for ith individual,<br />
the regression will use the observed claim number Yi (endogeneous) and its expected value<br />
coming from the zero-inflated negative binomial regression E(Y |Xi) (exogeneous).<br />
The numerical illustrations reveal that it is more relevant to cluster some <strong>de</strong>ductible values<br />
which are too few in the dataset. Actually, the <strong>de</strong>ductible is valued in {0, 150, 300, 500, 600,<br />
1000, 2000, 2500}. As 300 euros is the standard <strong>de</strong>ductible, very high <strong>de</strong>ductibles are rarely<br />
chosen. So, we choose to regroup <strong>de</strong>ductible values greater than 500 together. In Table 1.16,<br />
T β,<br />
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