<strong>the</strong> <strong>in</strong>crease <strong>of</strong> <strong>the</strong> probability <strong>of</strong> failure with time, was formulated.[...]The values <strong>of</strong> <strong>the</strong> frequencies <strong>of</strong> failures comprise a broken l<strong>in</strong>e.Their scatter <strong>in</strong>creases with t, a circumstance connected with a sharpdecrease <strong>of</strong> <strong>the</strong> area <strong>of</strong> <strong>in</strong>sulation, i. e., <strong>of</strong> <strong>the</strong> amount <strong>of</strong> experimentalmaterial.We are <strong>in</strong>terested <strong>in</strong> <strong>the</strong> values <strong>of</strong> probabilities p(t) <strong>of</strong> a failure <strong>of</strong> aunit area <strong>of</strong> <strong>in</strong>sulation aged t dur<strong>in</strong>g unit time (10 4 work<strong>in</strong>g hours,about 1.5 years). For small values <strong>of</strong> t <strong>the</strong> amount <strong>of</strong> experimentalmaterial is large, but p(t) <strong>the</strong>mselves are low, 0.01 – 0.02, so that <strong>the</strong>irdirect determ<strong>in</strong>ation through frequencies is fraught with very largeerrors. The mean square deviation <strong>of</strong> <strong>the</strong> frequency, µ i /S i , where µ i is<strong>the</strong> number <strong>of</strong> failures dur<strong>in</strong>g time <strong>in</strong>terval between (i – 1)-th <strong>and</strong> i-thtime units <strong>and</strong> S i , <strong>the</strong> correspond<strong>in</strong>g area <strong>of</strong> <strong>in</strong>sulation, is known to beequal top( ti)[1 − p( ti)]Siwhere t i =10 4 i hours. For t 1 = 10 5 p(t i ) ≈ 0.02, S i = 200, so thatdeviation is roughly 0.01 or 50% <strong>of</strong> p(t) itself.Then it is natural to attempt to heighten <strong>the</strong> precision <strong>of</strong> determ<strong>in</strong><strong>in</strong>gp(t) by smooth<strong>in</strong>g s<strong>in</strong>ce <strong>the</strong> estimation <strong>of</strong> this probability <strong>the</strong>n dependson all o<strong>the</strong>r experimental data. But <strong>the</strong>n, a statistical model isnecessary here. It is ra<strong>the</strong>r natural to consider <strong>the</strong> observed number <strong>of</strong>failures (1.2) as r<strong>and</strong>om variables with a Poisson distribution.Underst<strong>and</strong>ably,Eµ i = S i p(t i ).It is somewhat more difficult to agree that <strong>the</strong> magnitudes µ i are<strong>in</strong>dependent. Here, however, <strong>the</strong> follow<strong>in</strong>g considerations applicableto any rare events will help. Take for example µ 1 , µ 2 . Failure occurr<strong>in</strong>gdur<strong>in</strong>g <strong>the</strong> first <strong>in</strong>terval <strong>of</strong> time <strong>in</strong>fluences <strong>the</strong> behaviour <strong>of</strong> <strong>the</strong><strong>in</strong>sulation <strong>in</strong> <strong>the</strong> second <strong>in</strong>terval, but that action is only restricted to <strong>the</strong>failed mach<strong>in</strong>es whose portion was small. Hav<strong>in</strong>g admitted<strong>in</strong>dependence, <strong>the</strong> ma<strong>the</strong>matical model is completely given although itis connected not with <strong>the</strong> most convenient normal, but with <strong>the</strong>Poisson distribution. Then, <strong>the</strong> variancesvar µ i = Eµ i = S i p(t i )depend on probabilities p(t i ) which we <strong>in</strong>deed aim to derive. Atransformation to magnitudesv = 2 µ(2.1)iiessentially equalizes <strong>the</strong> variances <strong>and</strong> <strong>the</strong>refore helps.These magnitudes v 1 , v 2 , ..., v n from which we later return tomagnitudes (1.2) are smoo<strong>the</strong>d. The smooth<strong>in</strong>g itself is easy <strong>in</strong> essence58
ut some ma<strong>the</strong>matical tricks described <strong>in</strong> detail elsewhere (Belova etal 1965, 1967) are applied.The approximate expressionp(t i ) = p(x i ) ≈ (1/4)[b 0 – 0.1333b 2 + b 2 x 2 ] 2 + 0.35/S i , x i = t i /22,where t i is measured <strong>in</strong> <strong>the</strong> selected <strong>in</strong>tervals <strong>of</strong> time <strong>and</strong> <strong>the</strong> last termis necessary for allow<strong>in</strong>g for <strong>the</strong> systematic error that occurred whentransferr<strong>in</strong>g to v i (2.1) should be considered f<strong>in</strong>al.Estimates for b 0 <strong>and</strong> b 2 <strong>and</strong> <strong>the</strong>ir variances arebˆ = 0.225, bˆ = 0.20, var bˆ = 2.12⋅ 10 , var bˆ= 44.5⋅10 .−4 −40 2 0 2The magnitudes 0.35/S i are smoo<strong>the</strong>d by a certa<strong>in</strong> polynomial.Careful statistical work concern<strong>in</strong>g probabilities <strong>of</strong> failures shouldapply our answer exactly <strong>in</strong> <strong>the</strong> provided form. However, it is not vividenough <strong>and</strong> we have <strong>the</strong>refore represented it <strong>in</strong> a simplified way. Aconfidence rectangle for (b 0 , b 2 ) with an 80% coefficient was <strong>the</strong>refore<strong>in</strong>dicated with curves p 1 (t), p 2 (t), p 3 (t) added. Curve p 2 (t) provides <strong>the</strong>best estimate <strong>of</strong> <strong>the</strong> real probability <strong>of</strong> failure which we are able to<strong>of</strong>fer. It corresponds to <strong>the</strong> estimates <strong>of</strong> b 0 <strong>and</strong> b 2 . The o<strong>the</strong>r curves areobta<strong>in</strong>ed if <strong>the</strong> real po<strong>in</strong>t (b 0 , b 2 ) is replaced by <strong>the</strong> left lower <strong>and</strong> rightupper vertices <strong>of</strong> <strong>the</strong> confidence rectangle respectively. They providean idea about <strong>the</strong> order <strong>of</strong> <strong>the</strong> possible error <strong>of</strong> curve p 2 (t) but, strictlyspeak<strong>in</strong>g, are not <strong>the</strong> boundaries <strong>of</strong> <strong>the</strong> confidence region for <strong>the</strong> truecurve. The confidence region for p(t) can be constructed <strong>in</strong> differentways. Strictly speak<strong>in</strong>g, it is not needed s<strong>in</strong>ce all <strong>the</strong> <strong>in</strong>formationapplied for construct<strong>in</strong>g it is summed <strong>in</strong> <strong>the</strong> mentionedvariances, var bˆˆ0<strong>and</strong> var b2.The region between p 1 (t) <strong>and</strong> p 3 (t) can beconsidered as some approximate (hav<strong>in</strong>g <strong>the</strong> adequate order) version<strong>of</strong> <strong>the</strong> confidence region.Various versions <strong>of</strong> check<strong>in</strong>g our model by statistical tests are <strong>of</strong>fundamental significance. In statistics, no check is exhaust<strong>in</strong>g but anumber <strong>of</strong> well passed tests never<strong>the</strong>less produces a feel<strong>in</strong>g <strong>of</strong>certitude <strong>in</strong> <strong>the</strong> results. We will dwell <strong>in</strong> detail on all <strong>the</strong>se checks.The simplest criterion is <strong>the</strong> study <strong>of</strong> <strong>the</strong> f<strong>in</strong>al result. Let us have agood look at <strong>the</strong> curve represent<strong>in</strong>g <strong>the</strong> dependence sought. Do not <strong>the</strong>actual data deviate too much? (The maximal among <strong>the</strong> 22 deviationsis µ 20 = 4 <strong>and</strong> accord<strong>in</strong>g to <strong>the</strong> Poisson formula P{µ 20 ≥ 4} ≈ 0.12.) Initself, this is not especially significant, <strong>and</strong> for <strong>the</strong> maximal <strong>of</strong> 22deviations with only 1/22 ≈ 0.05, it is quite acceptable. [...]It is possible to compile an expression similar to <strong>the</strong> sum <strong>of</strong> <strong>the</strong>squares <strong>of</strong> deviations <strong>of</strong> <strong>the</strong> experimental data from <strong>the</strong> smooth curvep 2 (t). But it is better to deal with magnitudes v i (2.1) s<strong>in</strong>ce <strong>the</strong>irvariance does not essentially depend on <strong>the</strong> unknown probabilities p(t i )<strong>and</strong> is roughly equal to 1. In our case, <strong>the</strong> variance <strong>of</strong> <strong>the</strong> observationsis thus known almost exactly, a circumstance connected with <strong>the</strong>Poisson distribution, which depends only on one parameter ra<strong>the</strong>r thantwo as <strong>the</strong> normal law does. In general, <strong>the</strong> test apply<strong>in</strong>g <strong>the</strong> sum <strong>of</strong> <strong>the</strong>squares <strong>of</strong> deviations also shows that <strong>the</strong> f<strong>in</strong>al curve fits well enough.59
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Studies in the History of Statistic
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Introduction by CompilerI am presen
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(Lect. Notes Math., No. 1021, 1983,
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The Framingham investigation indeed
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or, for discrete observations,IT(ω
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What objections can be made? First,
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eliability and queuing are known to
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Kolman E. (1939 Russian), Perversio
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measurement is provided. Recently,
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which means that sooner or later th
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The foundations of the Mises approa
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A rather subtle arsenal is develope
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4.3. General remarks on §§ 4.1 an
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BibliographyAlimov Yu. I. (1976, 19
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processes are now going on in the s
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obtaining a deviation from the theo
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VIOscar SheyninOn the Bernoulli Law