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ST 522-001: Statistical Theory II
Solution to Lab Exercises - 4
Prepared by Chen-Yen Lin
Feb. 09, 2011
6.24; (i) When λ = 0, random variable X degenerates to 0. It follows immediately thatthis family is not complete. (ii) When λ = 1, to show this family is not complete,we can let g(0) = −e and g(X ) = 1, ∀x > 0. Then it can be shown that Eg(X ) =
g(0)e−1 + e−1∞
x=1h(x)x!
= −1 + 1 = 0.
6.26: (a) If P 0 consists two distributions N (θ1, 1) and N (θ0, 1). By Theorem 6.6.5 , a minimalsufficient statistic for P is
T (x) = pθ1 pθ0
= e−
nθ212
e−nθ202
exp
ni=1
xi(θ1 − θ0)
which is equivalent to X̄ (b) Similarly, consider a case in which P 0 consists only two distributions gamma(α, β 1)and gamma(α, β 0). By Theorem 6.6.25 , a minimal sufficient statistic for P 0 is
T (x) = β α0β α1
exp
−
ni=1
xi
1
β 0−
1
β 1
which is equivalent to n
i=1 X i.(c) Consider a case in which P 0 consists only two distributions U(0,θ1) and U(0,θ0).By Theorem 6.6.5 , the minimal sufficient statistic for P 0 is
T (X ) =θ−n1 I (X (n),∞)(θ1)
θ−n0 I (X (n),∞)(θ0)
which is X (n)
6.31(a) (i) When σ2 is known, it can be shown that X̄ is complete sufficient statistic for µ,whereas the distribution of (n − 1)S 2/σ2 does not depend on µ and therefore σ2 isancillary for µ. By Basu Theorem , X̄ ⊥ S 2.(ii) When σ2 is unknown but fixed, first observe that S 2 = (n− 1)−1
ni=1(X i−
X̄ )2 =(n − 1)−1
ni=1(Z i −
Z̄ )2, where Z i = X i − µ is N (0, σ2). Therefore, S 2 is still an
ancillary statistic. By Basu Theorem, X̄ ⊥ S 2 for unknown µ and fixed σ2. Since σ2 isarbitrary, this result can be extended to general unknown µ and σ2. (More discussioncan be found in Example 6.2.27.)
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6.31(c) (i) Given that X/Y and Y are independent, we have
EX k = E Y X Y
k
EX k = EY kE
X
Y
kEX k
EY k = E
X
Y
k
(ii) Since α is known, it can be argued that T = n
i=1 X i is complete sufficient forβ . Moreover, since X i comes from a scale family with standard variable Z i whose
distribution does not depend on β . It follows that X (i)
n
i=1 X iis ancillary for β . Therefore
E (X (i)|T ) = E
X (i)T
T |T
= E
X (i)T |T
E (T |T ) = E
X (i)T
T = E (X (i))
ET T
The last equality holds by using the result from (i).
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