Estimation, Evaluation, and Selection of Actuarial Models
Estimation, Evaluation, and Selection of Actuarial Models
Estimation, Evaluation, and Selection of Actuarial Models
Create successful ePaper yourself
Turn your PDF publications into a flip-book with our unique Google optimized e-Paper software.
107<br />
1− GAMMADIST(1/x, α, 1/θ,true). The estimates are ˆα =0.83556 <strong>and</strong> ˆθ =5, 113. The value <strong>of</strong><br />
the loglikelihood function is −363.92.<br />
Exercise 29 In each case the likelihood function is f(27)f(82) ···f(243)[1 − F (250)] 13 . The following<br />
table provides the estimates for both the original <strong>and</strong> censored data sets.<br />
Model Original Censored<br />
exponential ˆθ =1, 424.4 ˆθ =594.14<br />
gamma ˆα =0.55616, ˆθ =2, 561.1 ˆα =1.5183, ˆθ = 295.69<br />
inv. exponential ˆθ =197.72 ˆθ =189.78<br />
inv. gamma ˆα =0.70888, ˆθ = 140.16 ˆα =0.41612, ˆθ =86.290<br />
The censoring tended to disguise the true nature <strong>of</strong> these numbers <strong>and</strong> in general had a large impact<br />
on the estimates.<br />
Exercise 30 The calculations are done as in the example, but with θ unknown. The likelihood must<br />
be numerically maximized. For the shifted data the estimates are ˆα =1.4521 <strong>and</strong> ˆθ =907.98. The<br />
two expected costs are 907.98/0.4521 = 2, 008 <strong>and</strong> 1, 107.98/0.4521 = 2, 451 for the 200 <strong>and</strong> 400<br />
deductibles respectively. For the unshifted data the estimates are ˆα =1.4521 <strong>and</strong> ˆθ = 707.98. The<br />
three expected costs are 707.98/0.4521 = 1, 566, 2,008, <strong>and</strong> 2, 451 for the 0, 200, <strong>and</strong> 400 deductibles<br />
respectively. While it is always the case that for the Pareto distribution the two approaches produce<br />
identical answers, that will not be true in general.<br />
Exercise 31 Thesametablecanbeused. Theonlydifference is that observations that were<br />
surrenders are now treated as x-values <strong>and</strong> deaths are treated as y-values. Observations that ended<br />
at 5.0 continue to be treated as y-values. Once again there is no estimate for a Pareto model. The<br />
gamma parameter estimates are ˆα =1.229 <strong>and</strong> ˆθ =6.452.<br />
Exercise 32 The contribution to the likelihood for the first five values (number <strong>of</strong> drivers having<br />
zero through four accidents) is unchanged. However, for the last seven drivers, the contribution is<br />
[Pr(X ≥ 5)] 7 =[1− p(0) − p(1) − p(2) − p(3) − p(4)] 7<br />
<strong>and</strong> the maximum must be obtained numerically. The estimated values are ˆλ = 0.16313 <strong>and</strong><br />
ˆq =0.02039. These answers are similar to those for Example 2.36 because the probability <strong>of</strong> six or<br />
more accidents is so small.<br />
Exercise 33 There are four cases, with the likelihood function being the product <strong>of</strong> the probabilities<br />
for those cases raised to a power equal to the number <strong>of</strong> times each occurred. The following table<br />
provides the probabilities.<br />
Event<br />
Probability<br />
F (1)−F (0.4)<br />
1−F (0.4)<br />
Observed at age 35.4 <strong>and</strong> died<br />
Observed at age 35.4 <strong>and</strong> survived 1 − 0.6w<br />
Observed at age 35 <strong>and</strong> died F (1) = w<br />
Observed at age 35 <strong>and</strong> survived 1 − w<br />
The likelihood function is<br />
µ 0.6w<br />
L =<br />
1 − 0.4w<br />
<strong>and</strong> its logarithm is<br />
= w−0.4w<br />
1−0.4w = 1−0.4w<br />
0.6w<br />
1−0.4w = 1−0.4w<br />
1−w<br />
6 µ 1 − w 4<br />
w 8 (1 − w) 12 ∝ w14 (1 − w) 16<br />
1 − 0.4w<br />
(1 − 0.4w) 10<br />
l =14lnw +16ln(1− w) − 10 ln(1 − 0.4w).