The individual Poisson term is denoted as g( x, m) = Exp ( −m) m / x! and the cumulative c x x Poisson as G( c, m) = ∑ Exp ( −m) m / x! . We also introduce h ( x, m) = m / x! . Further the x= 0 Poisson probability of <strong>acceptance</strong> at ( p , p ,..., p ) , for the Plan A with sample size n and 1 2 r <strong>acceptance</strong> number a , a ,..., a is denoted as: PA , ,..., ; , ,..., ) 1 2 r ( a1 a2 ar m1 m 2 mr and the corresponding probability of rejection at ( p 1, p2,..., pr ) as QA( a , a ,..., a ; m , m ,..., m ) 1 2 r 1 2 r = 1 − PA( a , a ,..., a ; m , m ,..., m ) . 1 2 r 1 2 r x For the D kind plan with sample size n and <strong>acceptance</strong> number k the probability of <strong>acceptance</strong> at ( p , p ,..., p ) is denoted as PD ( k, m) . The corresponding probability of 1 2 r rejection at ( p , p ,..., p ) is denoted by QD ( k, m) . 1 2 r For given values of γ 1 , γ 2 the regret function defined in equation ( 2.2.9 ) for lots of size N using an A kind, with sample size n and with <strong>acceptance</strong> numbers ( a , a ,..., a ) is written as : 1 2 r RA( n; a , a ,..., a 1 2 r ) = n + ( N − n)[ γ QA( a , a ,..., a ; m , m , a , a ,..., a m ) + γ PA( a , a ,..., a ; m' , m' ,..., m' 1 1 2 r 1 2 1 2 r r 2 1 2 r 1 2 r Similarly the regret function of the plan D with sample size n and <strong>acceptance</strong> number k : RD ( n, k ) = n + N − n)[ γ QD( k, m) + γ PD( k, ')] ( 1 2 m )] 2.3.2 Situation 1 Theorem (2. 3.1) Assume γ 1 , γ 2 , N , p, p' to be given. Given an optimal D plan with parameters (k, n), the regret function value of the plan A with <strong>acceptance</strong> criterion: x() i ≤ k −1; for i = 1, 2,…,r-1; is less than the regret function value of the plan D (k, n) if k k + 1 [ p '( r − 1) / p( r −1) ] > ( p' / p) …. (2.3.1) Proof: Since D (n, k) is an optimal plan RD (n, k+1) - RD (n, k) ≥ 0 ⎛ γ k + 1 ⎞ ⎜ 2 ⎟ − ( m′−m) ⎛ m′ ⎞ e ⎜ ⎟ > 1 …. (2.3.2) ⎝ γ 1 ⎠ ⎝ m ⎠ Now RD (n; k) - RA (n; a 1 = k-1, a 2 = k-1 ,..., a r-1 = k-1, a r = k) / (N-n) = γ2 [ g ( k,m′ ( r 1) ) g (0,m′ r )] − γ1 [ g ( k,m( r 1 ) ) g (0,mr )] − − 95
From (2.3.2) we observe that γ 2 1 g ( k , m' γ g ( k , m ( r −1) ( r −1) ) g (0, m' ) ) g ( 0, m) ) > γ γ 2 1 − ( m ′− m ) e k + 1 ≥ [ m′ / m] 1 This implies , RD (n; k) > RA (n; a 1 = k-1,..., a r-1 = k-1, a r = k). (Proved) Remarks: A. The condition (2.3.1) is a sufficient condition and holds if ( p ′ / p′ ) < ( p / p ) r ( r−1) r ( r −1) B. For r = 2 the condition (2.3.1) becomes ( p k k + 1 ′ 1 / p 1 ) > ( p ′ / p ) For r = 2 this implies p ′ p 1 > 1 . p′ p We now try to obtain more general results. 2.3.3 Situation 2 Let us consider the set of A <strong>plans</strong> with <strong>acceptance</strong> criteria x ≤ a for i = 1, 2,..., r-1 x ( i ) r − 1 ( r ) ≤ a r . Note that the probability of <strong>acceptance</strong> at a process average p = ( p1 ,..., pr ) for this plan is PA ( a1 , a 2 ,..., a r ; m1 , m 2 ,...,mr ) = a a −x r = ∑ − 1 r ( r .... ∑ − 1) r ∏ g( x i , m i ) x = x = 0 i= 1 1 0 r a r ∑ − 1 = g ( x( r − ), m x( r ) − 1 = 0 ar − x 1 ( r −1) ) ∑ x = 0 r ( r−1) ( x r , m r ) g ... (2.3.3) Theorem (2.3.2) Let n, a r-1 , a r be the optimal parameters with <strong>acceptance</strong> criterion specified at the beginning of the section 2.3.4, for a given lot size N, γ 1 , γ 2 , p, p' etc. and assumption a r-1 ≥ 1. If we now construct a plan with the same sample size but with <strong>acceptance</strong> criterion changed to: x ( r − 2 ) ≤ a r − 1 − 1 , x( r − 1) ≤ a r −1 , x( r ) ≤ a r then the latter plan will have lesser regret value than the former plan, optimal in the specified set up, if ′ r −1 [ ( r −2 ) p( r −2 ) / p ] a > [ p ′ ( r −1) / p ( r −1) ] a r −1 + 1 ... (2.3.4) 96
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Multiattribute acceptance sampling
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e) the cost functions are linear an
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Contents 0.1 Purpose of sampling in
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Part 0 : Introduction 0.1 Purpose o
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procurement of materials of the US
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0.4 Scope of the present inquiry 0.
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0.4.6 A generalized acceptance samp
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equals to p i in the long run. We a
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m j , r∏ −P C j ′ = g(x j , m
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show that if we increase c 2 keepin
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independence and mutually exclusive
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different sampling schemes in terms
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curves i.e. the OC curve as a funct
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0.5.3 Part3 Bayesian multiattribute
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K(N, n)/(A 1 − R 1 ) = nk ′ s +
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example, a sample of finished garme
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...(1.1.2) If now X i is assumed to
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(i) Poisson as approximation to bin
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1.2 Multiattribute sampling schemes
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We take this case and the case of t
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