Ohrimenko+ / Ross S. A First Course in Probability_ Solutions Manual
.pdf35.(a) Let X1 denote the number of nonspades preceding the first ace and X2 the number of nonspades between the first 2 aces. It is easy to see that
P{X1 = i, X2 = j} = P{X1 = j, X2 = i}
and so X1 and X2 have the same distribution. Now E[X1] = 3j and so E[2 + X1 + X2] = 1065 .
(b)Same method as used in (a) yields the answer 5 39 +1 =
14
485 by the results of Example
26514 .
(c)Starting from the end of the deck the expected position of the first (from the end) heart is, from Example 3j, 1453 . Hence, to obtain all 13 hearts we would expect to turn over
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=−36n
37.Let Wi, i = 1, 2, denote the ith outcome.
Cov(X, Y) = Cov(W1 + W2 , W1 − W2)
=Cov(W1, W1) − Cov(W2, W2)
=Var(W1) − Var(W2) = 0
38.E[XY] = ∞∫∫x y2e−2xdydx
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39.Cov(Yn, Yn) = Var(Yn) = 3σ2
Cov(Yn, Yn+1) = Cov(Xn + Xn+1 + Xn+2, Xn+1 + Xn+2 + Xn+3)
= Cov(Xn+1 + Xn+2, Xn+1 + Xn+2) = Var(Xn+1 + Xn+2) = 2σ2 Cov(Yn, Yn+2) = Cov(Xn+2, Xn+2) = σ2
Cov(Yn, Yn+j) = 0 when j ≥ 3
40. fY(y) = e−y ∫1y e−x / ydx = e−y . In addition, the conditional distribution of X given that Y = y is exponential with mean y. Hence,
E[Y] = 1, E[X] = E[E[X Y]] = E[Y] = 1
Since, E[XY] = E[E[XY Y]] = E[YE[X Y]] = E[Y2] = 2 (since Y is exponential with mean 1, it follows that E[Y2] = 2). Hence, Cov(X, Y) = 2 − 1 = 1.
41.The number of carp is a hypergeometric random variable.
E[X] = 1060 = 6
Var(X) = |
20(80) 3 7 |
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Chapter 7 |
109 |
42. |
(a) Let Xi = 1 |
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E[XiXj] = P{Xi = 1, Xj = 1} = P{Xi = 1}P{Xj = 1 X2 = 1} |
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43.E[R] = n(n + m + 1)/2
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The above follows from Example 3d since when F = G, all orderings are equally likely and the problem reduces to randomly sampling n of the n + m values 1, 2, …, n + m.
110 |
Chapter 7 |
44.From Example 8l n +nm + nnm+ m . Using the representation of Example 2l the variance can be computed by using
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Cov(X1 + X2 , X2 + X3 ) |
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46. |
E[I1I2] = ∑E[I1I2 |
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bank rolls i]P{bank rolls i} |
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i=2
=∑(P{roll is greater than i})2 P{bank rolls i}
i
=E[I12 ]
≥ (E[I1])2
=E[I1] E[I2]
47.(a) It is binomial with parameters n − 1 and p.
(b)Let xi,j equal 1 if there is an edge between vertices i and j, and let it be 0 otherwise. Then,
∑k ≠i Xi,k , and so, for i ≠ j
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Cov(Di, Dj) = Cov |
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= ∑∑Cov(Xi,k , X r, j )
k ≠i r ≠ j
=Cov(Xi, j , Xi, j)
=Var(Xi, j)
=p(1 − p)
where the third equality uses the fact that except when k = j and r = i, Xi ,k and Xr, j are independent and thus have covariance equal to 0. Hence, from part (a) and the preceding we obtain that for i ≠ j,
ρ(Di, Dj) = |
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Chapter 7 |
111 |
48.(a) E[X] = 6
(b)E[X Y = 1] = 1 + 6 = 7
(c)11 + 2 4 1 + 3 4 2 1 + 4 4 3 1 + 4 4 (5 + 6) 5 5 5 5 5 5 5 5
49.Let Ci be the event that coin i is being flipped (where coin 1 is the one having head probability .4), and let T be the event that 2 of the first 3 flips land on heads. Then
P(C1 T) = |
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Now, with Nj equal to the number of heads in the final j flips, we have
E[N10 T] = 2 + E[N7 T]
Conditioning on which coin is being used, gives
E[N7 T] = E[N7 TC1]P(C1T) + E[N7TC2]P(C2 T) = 2.8(.395) + 4.9(.605) = 4.0705 Thus, E[N10 T] = 6.0705.
50. |
fX Y(x y) = |
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e−x / y , 0 < x < ∞ |
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Hence, given Y = y, X is exponential with mean y, and so
E[X 2 Y = y] = 2y2
51. |
fX Y(x y) = |
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y
E[X 3 Y = y] = ∫x3 1y dx = y3 / 4
0
52.The average weight, call it E[W], of a randomly chosen person is equal to average weight of all the members of the population. Conditioning on the subgroup of that person gives
r |
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member of subgroup i]pi = ∑wi pi |
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112 |
Chapter 7 |
53.Let X denote the number of days until the prisoner is free, and let I denote the initial door chosen. Then
E[X] = E[X I = 1](.5) + E[X I = 2](.3) + E[X I = 3](.2)
=(2 + E[X])(.5) + (4 + E[X])(.3) + .2
Therefore,
E[X] = 12
54.Let Ri denote the return from the policy that stops the first time a value at least as large as i appears. Also, let X be the first sum, and let pi = P{X = i}. Conditioning on X yields
12
E[R5] = ∑E[R5 X = i}pi
i=2
12
= E[R5)(p2 + p3 + p4) + ∑ipi − 7p7
i=5
=366 E[R5 ] + 5(4/36) + 6(5/36) + 8(5/36) + 9(4/36) + 10(3/36) + 11(2/36) + 12(1/36)
6
= 36 E[R5 ] + 190/36
Hence, E[R5] = 19/3 ≈ 6.33. In the same fashion, we obtain that
E[R6] = 1036 E[R6 ] + 361 [30 + 40 + 36 + 30 + 22 + 12]
implying that
E[R6] = 170/26 ≈ 6.54
Also,
E[R8] = |
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E[R ] + |
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(140) |
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or,
E[R8] = 140/21 ≈ 6.67
In addition,
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E[R ] + |
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or
E[R9] = 100/16 = 6.25
Chapter 7 |
113 |
And
E[R10] = |
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E[R ] + |
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(64) |
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or
E[R10] = 64/12 ≈ 5.33
The maximum expected return is E[R8].
55.Let N denote the number of ducks. Given N = n, let I1, …, In be such that
1 if duck i is hit Ii = 0 otherwise
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N = n, each hunter will independently hit duck i with probability .6/n.
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56. |
Let Ii = 1 |
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57.E ∑N Xi = E[N]E[X ] = 12.5
i=1
58.Let X denote the number of flips required. Condition on the outcome of the first flip to obtain.
E[X] = E[X heads]p + E[x tails](1 − p)
=[1 + 1/(1 − p)]p + [1 + 1/p](1 − p)
=1 + p/(1 − p) + (1 − p)/p
114 |
Chapter 7 |
59.(a) E[total prize shared] = P{someone wins} = 1 − (1 − p)n+1
(b)Let Xi be the prize to player i. By part (a)
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But, by symmetry all E[Xi] are equal and so
E[X] = [1 − (1 − p)n+1]/(n + 1)
(c)E[X] = p E[1/(1 + B)] where B, which is binomial with parameters n and p, represents the number of other winners.
60.(a) Since the sum of their number of correct predictions is n (one for each coin) it follows that one of them will have more than n/2 correct predictions. Now if N is the number of correct predictions of a specified member of the syndicate, then the probability mass function of the number of correct predictions of the member of the syndicate having more than n/2 correct predictions is
P{i correct} = P{N = i} + P(N = n − i} i > n/2
=2P{N = i}
=P{N = i N > n/2}
(b)X is binomial with parameters m, 1/2.
(c)Since all of the X + 1 players (including one from the syndicate) that have more than n/2 correct predictions have the same expected return we see that
(X + 1) Payoff to syndicate = m + 2 implying that
E[Payoff to syndicate] = (m + 2) E[(X + 1)−1]
(d) This follows from part (b) above and (c) of Problem 56.
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pF(x) |
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61. |
(a) P(M ≤ x) = ∑P(M ≤ x |
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(b)P(M ≤ x N = 1) = F(x)
(c)P(M ≤ x N > 1) = F(x)P(M ≤ x)
(d)P(M ≤ x) = P(M ≤ x N = 1)P(N = 1) + P(M ≤ x N > 1)P(N > 1)
=F(x)p + F(x)P(M ≤ x)(1 − p)
again giving the result
≤ pF(x)
P(M x) = 1−(1− p)F(x)
Chapter 7 |
115 |
62. The result is true when n = 0, so assume that
P{N(x) ≥ n} = xn/(n − 1)!
Now,
P{N(x) ≥ n + 1} = ∫1 P{N(x) ≥ n +1 U1 = y}dy
0
= ∫x P{N(x − y) ≥ n}dy
0
= ∫x P{N(u) ≥ n}du
0
= ∫x un−1 /(n −1)! du by the induction hypothesis
0
= xn/n!
which completes the proof.
∞ |
∞ |
∞ |
(b) E[N(x)] = ∑P{N(x) > n = ∑P{N(x) ≥ n +1} = ∑xn / n! = ex |
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63.(a) Number the red balls and the blue balls and let Xi equal 1 if the ith red ball is selected and let it by 0 otherwise. Similarly, let Yj equal 1 if the jth blue ball is selected and let it be 0 otherwise.
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Now,
E[Xi] = E[Yj] = 12/30 |
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Cov(X, Y) = 80 10 |
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116 |
Chapter 7 |
(b)E[XY X] = XE[Y X] = X(12 − X)8/20
where the above follows since given X, there are 12-X additional balls to be selected from among 8 blue and 12 non-blue balls. Now, since X is a hypergeometric random variable it follows that
E[X] = 12(10/30) = 4 and E[X 2] = 12(18)(1/3)(2/3)/29 + 42 = 512/29 As E[Y] = 8(12/30) = 16/5, we obtain
E[XY] = 52 (48 −512/ 29) = 352/29,
and
Cov(X, Y) = 352/29 − 4(16/5) = −96/145
64.(a) E[X] = E[X type 1]p + E[X type 2](1 − p) = pµ1 + (1 − p)µ2
(b) Let I be the type.
E[X I] = µI , Var(X I) = σI2 Var(X) = E[σI2 ] + Var(µI )
=pσ12 + (1− p)σ22 + pµ12 + (1− p)µ22 −[ pµ1 + (1− p)µ2 ]2
65.Let X be the number of storms, and let G(B) be the events that it is a good (bad) year. Then
E[X] = E[X G]P(G) + E[X B]P(B) = 3(.4) + 5(.6) = 4.2
If Y is Poisson with mean λ, then E[Y 2] = λ + λ2. Therefore,
E[X 2] = E[X 2 G]P(G) + E[X 2 B]P(B) = 12(.4) + 30(.6) = 22.8
Consequently,
Var(X) = 22.8 − (4.2)2 = 5.16
66. |
E[X 2] = |
1 |
{E[X 2 |
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Y =1] + E[X 2 |
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Y = 2] + E[X 2 |
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Y = 3]} |
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=13{9 + E[(5 + X )2 ] + E[(7 + X )2 ]}
=13{83 + 24E[X ] + 2E[X 2 ]}
=13{443 + 2E[X 2 ]} since E[X] = 15
Hence,
Var(X) = 443 − (15)2 = 218.
Chapter 7 |
117 |