Asymptotic Methods in Statistical Inference - Statistics Centre

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198 • Example. A process produces units ∼ (0 1) when in control (w.p. ), and ∼ ( 1) ( 6= 0) when not in control (w.p. 1 − ). Then ∼ (; θ) =()+(1−)(−) θ =( ) 0 We calculate = ()−(−) =(1−)(−)(−) so ˙ (θ) = X =1 (Ã ( ) − ( − ) (1 − )( − )( − ) ! /( ; θ) and we seek a solution to ˙ (θ) =0. If e θ is √ - consistent and ˆθ is the one-step improvement, then √ ³ˆθ − θ 0´ → ³ 0 I −1 ( 0 )´. To get eθ we can use the ‘method of moments’: if θ = g ( 1 ) is a continuous function of the moments = h i ,andif = ˆ h i = P is the corresponding sample moment, then eθ = g ( 1 )isconsistent,andis √ -consistent if g is differentiable. This follows from the joint )
199 asymptotic normality of the sample moments: by the CLT, √ (1 − 1 ··· − ) 0 → (0 Σ) where = h i = + − . In this example = (1− ) h 2i = +(1− )(1 + 2 )=1+(1− ) 2 2 = h 2i − 2 =1+(1 − )2 Solving for gives = 2 − 1 2 + 2 − 1 = 2 + 2 − 1 and so ˜ = 2 − 1 ¯ 2 + 2 − 1 ˜ = ¯ 2 + 2 − 1 ¯ Although ˜ may not be in (0 1), it is with probability → 1. To see this let be such that 1 − . Then (0 ˜ 1) ≥ (|˜ − | ≤ ) → 1
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STATISTICS 665 ASYMPTOTIC METHODS I
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II LARGE-SAMPLE INFERENCE 42 5 Intr
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V LIKELIHOOD METHODS 169 19 Maximum
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Part I PROBABILISTIC PRELIMINARIES
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The ‘rate’ of convergence refer
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11 imagine ‘large’ but remain
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13 • For the ( ) distribution,
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15 —Corollary1: → If h (
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17 2. Slutsky’s Theorem; conseque
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— By the CLT, − q (1 − ) 1
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21 • Corollary 1: If → the
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23 • First an application. Let 2
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25 with d.f. (), then there is a
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27 next lecture), = 1− " ( )+
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29 • CLT via the Edgeworth expans
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31 (why?) with ‘cumulant generati
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Thus in (3.2), () () isthec.f.of
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35 • Delta method. Suppose that
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37 • Uniformity—read§2.6 • C
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39 suppose that → 0. Then X =1
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41 • Under this condition ˆ is (
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43 5. Introduction to asymptotic te
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45 • We often work instead with t
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47 • Two-sample problems. Suppose
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49 • Example 2: 1 ∼ P(),
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51 term is Ã √ ˆ ( ( 0 )
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53 • More useful is to study the
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55 • Example: t-test of a mean.
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57 • Efficacy. Test : = 0 vs.
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59 Put = − and test for tre
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61 7. Relative efficiency • Relat
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• The constraint (1) ∼ (2)
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65 =1. Theefficacy is = 0 q (0)
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67 • Example 3. In this example
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69 Proof of ‘ 1’: From 1 − (
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71 • We will consider only ‘lev
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73 • Example 1. Suppose we (mista
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75 To see this take 0 = 0 for simp
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77 The numerator of is normally d
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79 9. Confidence intervals • X =(
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81 • Example. 1 ∼ () ( 0);
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83 • A strong CI on a population
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85 • A more involved example of a
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87 We exhibit 1 () 2 () → 1−
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10. Point estimation; Asymptotic re
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91 Recall that if 0 () 6= 0 (assum
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93 where (with being a bound on |
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• Asymptotic Relative Efficiency.
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97 0.0 0.1 0.2 0.3 0.4 0.5 0.6 -3 -
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99 that then √ ³ ¯ − ´
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101 — This is also the ARE of the
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103 We minimize Z h 2 ()+2 2 ()
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105 In a broad class of cases, comp
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107 The ARE of the estimates consid
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109 We have lim →∞ { ∗ () −
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111 13. Random vectors; multivariat
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113 • X () () → c (constant)
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115 • Multivariate normality. We
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117 • If X ∼ (μ Σ) then an
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119 14. Multivariate applications
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121 One can eliminate the last elem
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123 have = (|)+ ¯ (| ¯) =
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125 at = 1. In this latter case Ã
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127 Proof: Write Then +1 = − X
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129 15. Expectation functionals; U-
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131 • A closely related estimate,
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1≤≤ 133 — e.g. = 2; let =
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135 • Rao-Blackwell Theorem: We c
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137 • Here we get the variance of
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139 16. Asymptotic normality of U-s
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141 Under , ( + ) = () ∼ (0 1)
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143 • Proofofclaim1: [( − ) |
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145 • V-statistics. Recall that i
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Page 149 and 150: 149 By using the fact that | 2 −
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Page 167 and 168: 167 • Indeed, since ( ) has plu
Page 169 and 170: 169 Part V LIKELIHOOD METHODS
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Page 173 and 174: 173 • Assume: (C1) Identifiabilit
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Page 187 and 188: 187 Claim: (i) (ii) (iii) 0 ( 0 )
Page 189 and 190: 189 Define the ‘scores’ ( −
Page 191 and 192: 191 • The MLE is not the only eff
Page 193 and 194: 193 The variance-minimizing choice
Page 195 and 196: 195 • Multiparameter likelihood e
Page 197: 197 • Efficiency. Under appropria
Page 201 and 202: 201 • Likelihood ratio test. Put
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Page 205 and 206: 205 • Example. 1 ∼ Logistic,
Page 207 and 208: 207 • Multiparameter inferences.
Page 209 and 210: 209 For testing, I( 0 ) is replaced
Page 211 and 212: 211 24. Examples Example: 1 ∼
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Page 215 and 216: 215 • The likelihood ratio statis
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Page 221 and 222: 221 25. Higher order asymptotics
Page 223 and 224: 223 As in Lecture 10, cov h i 2 h
Page 225 and 226: 225 • The normal approximation, a
Page 227 and 228: 227 By uniqueness of m.g.f.s, (;
Page 229 and 230: 229 • Example 2. Let = P 1 w
Page 231: 231 • The error of Saddlepoint
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