Strength modeling using Weibull distributions
|
|
- Derek Cannon
- 5 years ago
- Views:
Transcription
1 Joural of Mechaical Sciece Techology Joural of Mechaical Sciece Techology 22 (2008) 247~254 Stregth modelig usig Weibull distributios Saralees Nadarajah,* Samuel Kotz 2 School of Mathematics, Uiversity of Machester, Machester M60 QD, U.K. 2 Departmet of Egieerig Maagemet Systems Egieerig, The George Washigto Uiversity, Washigto DC 20052, U.S.A. (Mauscript Received March 8, 2006, Revised April 24, 2008; Accepted April 24, 2008) Abstract The two-parameter Weibull distributio is the most popular model for material stregth. However, it may ot be a good model for all materials over a wide rage of sizes. I this ote, a comprehesive review of the kow variatios of the two-parameter Weibull distributio is provided to help providig better modelig. Over 20 variatios are reviewed. The appropriateess of the variatios is discussed as models for brittle versus ductile stregth. A compariso study of a selectio of the variatios is also provided. It is hoped that this review will also serve as a importat referece ecourage developmets of further variatios of the two-parameter Weibull distributio. Keywords: Material stregth; Statistical modelig; Weibull distributio Itroductio The most widely used distributio for characterizig material stregth is the two parameter Weibull distributio. If X is a rom variable represetig some material stregth the the probability distributio fuctio (pdf) the cumulative distributio fuctio (cdf) of the Weibull distributio ca be expressed as px ( ) = λ( λx) exp{ ( λx) } () Px ( ) = exp{ ( λx) }, (2) * Correspodig author. Tel.: , Fax.: address: saralees.adarajah@machester.ac.uk DOI 0.007/s respectively, for x > 0, λ > 0 > 0. The parameters λ are referred to as the scale shape parameters, respectively. The Rayleigh Levy distributios are the particular cases of ()-(2) for = 2 = /2, respectively. The th momet of X associated with ()-(2) is E( X ) = λ Γ (( + ) / ). While ()-(2) has bee show to be a good approximatio for the distributio of average stregth of may brittle materials, it may ot be a good represetatio for all materials over a wide rage of sizes. This pheomeo is especially sigificat because it might result i a serious stregth overestimatio or uderestimatio. This problem could be remedied by usig oe of the may geeralizatios of ()-(2) that have bee proposed i the statistical literature. The aim of this ote is to help this by providig a comprehesive review of the kow variats of ()-(2). Over 20 variatios of ()-(2) are reviewed-formulas for the distributio fuctios the momets are give for each. Apart from helpig to provide better modelig, it is hoped that this review will serve as a importat referece ecourage developmets of further geeralizatios of ()-(2). We also discuss the appropriateess of the variatios as models for brittle versus ductile stregth provide a compariso study of a selectio of the variatios usig six data sets o fracture toughess. 2. Reflected Weibull distributio If X has the Weibull distributio give by () the -X is said to have the reflected Weibull distribu-
2 248 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~254 tio. The pdf the cdf are give by p( x) ( x) = λ λ exp{ ( λx) } (3) Px ( ) = exp{ ( λx) } (4) respectively, for < x < 0, λ > 0 > 0. The associated mea the variace are λ Γ ( + / ) 2 2 λ { Γ (+ 2/ ) Γ (+ / )}, respectively. For further details of this distributio see Cohe []. 3. Double Weibull distributio A distributio made up by piecig () (3) together is the double Weibull distributio [2]. The pdf the cdf are give by px ( ) = ( λ / 2) λx exp{ λx } (5) (/ 2)exp{ λx}, if x< 0, Px ( ) = (6) (/ 2)exp{ λx}, if x 0, respectively, for < x <, > 0 λ > 0. The th momet correspodig to (5) is: λ Γ (( + ) /, if is eve, E( X ) = 0, if is odd. 4. Log Weibull distributio If X has theweibull distributio give by () the logx is said to have the logweibull distributio. The pdf the cdf take the forms x a x a px ( ) = exp exp exp b b b x a Px ( ) = exp exp, b (7) (8) respectively, for < x <, < a <, b > 0. The mea the variace of this distributio 2 are a γ b π b 2 /6, respectively, where γ deotes the Euler s costat. For further details see White [3]. 5. Iverse Weibull distributio If X has the Weibull distributio give by () the /X is said to have the iverse Weibull distributio. The pdf the cdf take the forms px ( ) x = λ exp{ ( x/ λ) } (9) Px ( ) = exp{ ( x/ λ) }, (0) respectively, for x > 0, > 0 λ > 0. The th momet correspodig to (9) is: E( X ) = λ Γ(( ) / ). This distributio is also referred to as the complemetary or the reciprocal Weibull distributio. For further details see Drapella [4] Mudholkar Kollia [5]. 6. Trucated Weibull distributio A doubly trucated versio of () is give by the pdf the cdf px ( ) qx ( ) = () Pb ( ) Pa ( ) Px ( ) Pa ( ) Qx ( ) = (2) Pb ( ) Pa ( ) respectively, for 0 a< x< b<, where px ( ) Px ( ) are give by () (2), respectively. The associated th momet is give by exp{( λb) } E( X ) = λ Γ +,( λb) exp{ ( λa) } Γ +, ( λa), where Γ (, ) is the complemetary icomplete gamma fuctio defied by ( a, x) a t exp( t) dt. x Γ = For further details about this distributio see McEwe Parresol [6]. 7. Marshall Olki s Weibull distributio Marshall Olki [7] proposed a exteded Weibull distributio give by the pdf νλ( λx) exp{ ( λx) } px ( ) = (3) ( ν)exp{ ( λx) } for x > 0, ν > 0, λ > 0 > 0. The Weibull distributio i () is the particular case of (3) for
3 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~ ν =. The cdf the th momet associated with (3) are: exp{ ( x) } Px ( ) = ν λ ( )exp{ ( x ) ν λ } k λ ( v) E( X ) = Γ, / k= 0 ( k + ) respectively, with the latter beig valid for ν. 8. distributio The pseudo Weibull distributio due to Voda [8] is give by the pdf + px ( ) = xλ { Γ ( + / )} exp{ ( λx) } (4) for x > 0, > 0 λ > 0. Note that this form is obtaied by multiplyig () by a additioal x term. The cdf the th momet correspodig to (4) are : γ( + /, ( λx) ) Px ( ) = Γ ( + / ) Γ ( + ( + ) / ) E( X) =, / λ Γ ( + / ) respectively, where γ (, ) deotes the icomplete gamma fuctio defied by γ x ( a, x ) t a = exp( t ) dt distributio Stacy [9] proposed a distributio with the pdf c c c px ( ) = c { Γ( )} x exp{ ( x/ ) } (5) for x > 0, c > 0, > 0 > 0. The Weibull distributio i () arises as the particular case of (5) for =. The cdf the th momet correspodig to (5) are: c x Px ( ) = { Γ( )} γ, E( X ) = Γ ( + / c)/ Γ ( ), respectively. A further extesio of (5) due to Ghitay [0] has the pdf give by ( ) ( m )/ + λ m 2 λ x + x x px ( ) = exp Γλ (( m ) /, ) for x > 0, > 0, > 0, λ > 0, m> 0 > 0, where Γ (, ) is defied by λ a y exp( y) Γ λ ( a, x) = dy. x λ ( y+ x) 0. Expoetiated Weibull distributio Mudholkar et al. [] itroduced the expoetiated Weibull distributio give by the pdf the cdf px ( ) a x exp{ ( x) }[ exp{ ( x) }] a Px ( ) = [ exp{ ( λx) }], (7) respectively, for x > 0, a > 0, > 0 λ > 0. The Weibull distributio i () is the particular case of (6) for a =. The th momet associated with (6) is give by λ = λ λ (6) ( a) i E( X) = aλ Γ +, ( + )/ i= 0 i!( i+ ) which ca be reduced to the simpler form E( X) ( a) a i = λ Γ + ( )/ + i= 0 i!( i+ ) if a is a iteger. For further details of this distributio see Mudholkar Hutso [2], Nassar Eissa [3] Nadarajah Gupta [4].. Xie et al. s weibull distributio Xie et al. [5] proposed a modificatio of the Weibull distributio give by the pdf the cdf x x x px ( ) = λ exp + λ exp (8) Px ( ) exp exp x = λ (9) ε for x > 0, λ > 0, > 0 > 0. The Weibull distributio i () arises as the limitig case of (8) as. Expressios for the momets associated with (8) caot be obtaied i closed form. However, if k/ = is a iteger the the kth momet ca be
4 250 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~254 expressed as ν k k ( λ) Γ( ν, λ) E( X ) = exp( λ) (20) ν for =, 2,..., where the derivative is evaluated as ν 0. For further details of this distributio see Che [6], Tag et al. [7], Wu et al. [8] Nadarajah [9]. 2. distributio Aother modificatio of the Weibull distributio developed by Lai et al. [20] is give by the pdf the cdf p( x) ( vx) x = λ + exp( νx)exp{ λx exp( νx} (2) Px ( ) = exp{ λx exp( νx)}, (22) respectively, for x > 0, λ > 0, > 0 ν > 0. The Weibull distributio i () is the particular case of (2) for ν = 0. The log-webiull distributio i (7) is the particular case of (2) for = Geeralized Weibull distributios Mudholkar Srivastava [2] Mudholkar et al. [] developed three differet geeralized Weibull distributios. The first of these has the pdf the cdf give by λ ( λx) / ν px ( ) = ν( λx) ν( λx) (23) / ν Px ( ) = ν( λx) (24) respectively, for 0 < x < (if ν 0 ), 0 < x < / λν (if ν > 0 ), λ > 0 > 0. The Weibull distributio i () arises as the limitig case of (23) for ν 0. The th momet associated with (23) is: / E( X ) ν = B (/ ν, / + ). The secod geeralizatio is give by the cdf / ν Px ( ) = ν( + x/ ) (25) for < x < (if < 0 ν < 0 ), < x < / ν (if < 0 ν > 0), < x < (if / > 0 ν < 0 ), < x< v (if > 0 ν > 0 ). The iverse Weibull (see Sectio 5) is a particular case of this distributio. The th momet associated with (25) is: k / E( X ) = ( ) ν B(/ ν, / + ). k= 0 k The third geeralizatio discussed i Mudholkar Srivastava [2] Mudholkar et al. [] is give by the cdf { x } exp ( + / ), if 0, Px ( ) = exp{ exp( x)}, if = 0 (26) for < x < (if < 0 ), < x < (if > 0 ) < x < (if = 0 ). For further details about these geeralizatios see Mudholkar Kollia [5]. 4. Four five-parameter weibull distributios Phai [22] developed a four-parameter Weibull distributio give by the cdf { λ } Px ( ) = exp [( x a)/( b x)] (27) for 0 a< x< b<, λ > 0 > 0. A fiveparameter extesio of this give by Kies [23] has the cdf 2 Px ( ) = exp { λ( x a) / b( x) } (28) for 0 a< x< b<, λ > 0, > 0 2 > Mixture Weibull distributios A additive twofold Weibull mixture distributio ca be expressed by the pdf p( x) = p ( x) + ( ) p ( x) (29) 2 for 0< <, where pi, i =, 2 could take the form of ay of the pdfs discussed above. The cdf correspodig to (29) is: Px ( ) = Px ( ) + ( ) P( x), 2 where P i is the cdf correspodig to pi. Multiplicative twofold mixtures ca be defied by the cdfs Px ( ) = PxP ( ) ( x) 2 Px ( ) = { Px ( )}{ P( x)} 2 for 0< < 0< <. Mixtures of more tha two compoets ca be defied i the obvious maer.
5 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~ Brittle vs Ductile stregth Suppose X, X2,, X are idepedet idetically distributed rom variables, represetig the stregth of items. If the distributio of max ( X, X2,, X ) belogs to the same distributio family of X, X2,, X the the distributio will be a appropriate model for ductile stregth. O the other h, if the distributio of mi ( X, X2,, X ) belogs to the same distributio family of X, X2,, X the the distributio will be a appropriate model for brittle stregth. Of the various Weibull distributios discussed i Sectios to 5, The followig will be appropriate models for brittle stregth: the stardweibull distributio (Eq. (2)); the log Weibull distributio (Eq. (8)); Xie et al. s Weibull distributio (Eq. (9)); Lai et al. s Weibull distributio (Eq. (22)); the geeralized Weibull distributios (Eqs. (24), (25) (26)); the four five parameterweibull distributios (Eqs. (27) (28)). The followig will be appropriate models for ductile stregth: the reflected Weibull distributio (Eq. (4)); the iverse Weibull distributio (Eq. (0)); the expoetiated Weibull distributio (Eq. (7)). The doubleweibull distributio give by (6) ca be used to model both brittle ductile stregths. 7. Compariso study I this sectio, we provide a compariso of the various Weibull distributios discussed i Sectios to 5. We use fracture toughess data from the six differet materials: Bi 2 Sr 2 CaCu 2 O 8+x, Alumia (Al 2 O 3 ), Silico Nitride (Si 3 N 4 ), Sialo (Si 6-x Al x O x N 8-x ), Pyroceram 9606, Titaium Diboride (TiB2). These data are take from the web site: For the iterest of the readers, we have reproduced the data i Table. Some summary statistics of the data are give i Table 2. Note that Bi 2 Sr 2 CaCu 2 O 8+x Sialo (Si 6-x Al x O x N 8-x ) are two of the toughest materials while Titaium Diboride (TiB 2 ) is the lightest material. We fitted eight of theweibull distributios to each of the six data sets: the stardweibull distributio (Eq. ()), iverse Weibull distributio (Eq. (9)), Marshall Olki s Weibull distributio (Eq. (3)), pseudo Weibull distributio (Eq. (4)), distributio (Eq. (5)), expoetiated Weibull Table. Fracture toughess data for six differet materials. Material Material Titaium Diboride (TiB 2 ) Fracture toughess data (i the uits of MPa m /2 ) 3.7,5.75,4.25,6.4,4.87,2.3,5.4,4.6,6,5.2, 5.36 Material 2 Pyroceram ,3.7,2.69,2.4,2.07,2.8,2.5,2.25 Material 3 Sialo (Si 6 x Al x O x N 8 x ) Material 4 Silico Nitride (Si 3 N 4 ) Material 5 Alumia (Al 2 O 3) 3.05,2.9,2.75,2.7,2.65,3.5,3.75,3.8,3.72, 3.52,3.44,3.26,2.99,2.79,3,3.8,3.66,3.2, 3.3,3.5,3.,4.65,3.42,3.38, ,7.2,3.2,4.96,7.8,6.59,4.9,4.,4.5,4.7, 3.2,2.7, ,5,4.9,6.4,5.,5.2,5.2,5,4.7,4,4.5,4.2, 4.,4.56,5.0,4.7,3.3,3.2,2.68,2.77,2.7, 2.36,4.38,5.73,4.35,6.8,.9,2.66,2.6,.68,2.04,2.08,2.3,3.8,3.73,3.7,3.28, 3.9,4,3.8,4.,3.9,4.05,4,3.95,4,4.5,4.5, 4.2,4.55,4.65,4.,4.25,4.3,4.5,4.7,5.5, 4.3,4.5,4.9,5,5.35,5.5,5.25,5.8,5.85,5.9, 5.75,6.25,6.05,5.9,3.6,4.,4.5,5.3,4.85, 5.3,5.45,5.,5.3,5.2,5.3,5.25,4.75,4.5,4.2, 4,4.5,4.25,4.3,3.75,3.95,3.5,4.3,5.4,5, 2.,4.6,3.2,2.5,4.,3.5,3.2,3.3,4.6,4.3,4.3, 4.5,5.5,4.6,4.9,4.3,3,3.4,3.7,4.4,4.9,4.9,5 Material 6 3.2,3.9,2.7,3.2,.9,.2,.8,.4,.8,2.9,2.8, Bi 2 Sr 2 CaCu 2 O 8+x 2.4 Table 2. Summary statistics of fracture toughess data. Mea Media Miimum Maximum Stard devi atio Material Material Material Material Material Material distributio (Eq. (6)), distributio (Eq. (8)) the distributio (Eq. (2)). The fittig of the distributios was performed by the method of maximum likelihood. For example, for fittig the stard Weibull distributio give by () we maximized L(, λ) = λ xi exp λ xi i= i= or equivaletly log L(, λ) = log + log λ + ( ) log xi λ x i i= i= (where x i, i =, 2,..., are the observed fracture toughess) with respect to the two parameters
6 252 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~254 Table 3. Fitted models estimates. Model Parameter estimates NLLH Material : Titaium Diboride (TiB 2 ) Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull Material 2: Pyroceram 9606 Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull Material 3: Sialo (Si 6 x Al x O x N 8 x ) Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull Material 4: Silico Nitride (Si 3 N 4 ) Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull Material 5: Alumia (Al 2 O 3 ) Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull Material 6: Bi 2 Sr 2 CaCu 2 O 8+x Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull ˆ =5.626 ˆλ =0.89 ˆ =2.920 ˆλ =4.047 ˆ =4.596, ˆλ =0.208 ˆ ν =2.800 ˆ =5.00 ˆλ =0.98 ˆ =0.23, ˆ =6.234 ĉ =6.394 ˆ =5.674, ˆ =0.64 â =0.24 ˆ =0.643, ˆ =0.909 ˆλ =0.002 ˆ =0.693, ˆλ =0.808 ˆ ν =3.688x0-6 ˆ =7.584 ˆλ =0.375 ˆ =8.673 ˆλ =2.334 ˆ =5.803, ˆλ =0.408 ˆ ν =2.849 ˆ =7.023 ˆλ =0.384 ˆ =97.34, ˆ =0.005 ĉ =0.742 ˆ =0.989, ˆ =3.675 â =4.638x0 3 ˆ =0.076, ˆ =0.677 ˆλ =0.000 ˆ =.582, ˆλ =0.00 ˆ ν =2.23 ˆ =6.000 ˆλ =0.287 ˆ =9.284 ˆλ =3.073 ˆ =5.049, ˆλ =0.329 ˆ ν =3.744 ˆ =6.57 ˆλ =0.295 ˆ =08.272, ˆ =0.007 ĉ =0.76 ˆ =.206, ˆ =.720 â = ˆ =0.052, ˆ =0.582 ˆλ =0.000 ˆ =7.433, ˆλ =9.22x0-5 ˆ ν =.927x0-6 ˆ =3.303 ˆλ =0.69 ˆ =2.990 ˆλ =4.72 ˆ =2.626, ˆλ =0.98 ˆ ν =2.68 ˆ =2.725 ˆλ =0.94 ˆ =4.008, ˆ =2.44 ĉ =.49 ˆ =2.099, ˆ =0.225 â =2.34 ˆ =0.00, ˆ =0.282 ˆλ =0.007 ˆ =0.73, ˆλ =0.859 ˆ ν =.332x0-6 ˆ =4.965 ˆλ =0.22 ˆ =3.024 ˆλ =3.62 ˆ =3.998, ˆλ =0.238 ˆ ν =2.808 ˆ =4.390 ˆλ =0.225 ˆ =0.80, ˆ =4.959 ĉ =5.690 ˆ =5.504, ˆ =0.206 â =0.837 ˆ =0.007, ˆ =0.393 ˆλ =0.000 ˆ =4.058, ˆλ =0.00 ˆ ν =0.200 ˆ =3.462 ˆλ =0.369 ˆ =2.899 ˆλ =.922 ˆ =2.795, ˆλ =0.428 ˆ ν =2.630 ˆ =2.883 ˆλ =0.48 ˆ =.230, ˆ =2.497 ĉ =3.047 ˆ =3.347, ˆ =0.374 â =.059 ˆ =0.00, ˆ =0.305 ˆλ =0.00 ˆ =3.487, ˆλ =0.03 ˆ ν =9.727x
7 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~ Table 4. Fitted models goodess of fit. Model Stard Weibull Iverse Weibull Marshall & Olki s Weibull Expoetiated Weibull Goodess of fit measure Material Material 2 Material 3 Material 4 Material 5 Material λ. The quasi-newto algorithm lm i the R software package (Deis Schabel, [24]; Schabel et al., [25]; Ihaka Getlema, [26]) was used to maximize the likelihood. A sample program i R for fittig () is illustrated below. Similar programs for fittig the other Weibull distributios ca be obtaied by cotactig the first author. #fittig of the stard Weibull model give by () for data cotai i x f<-fuctio (p) {alpha<-p [] lambda<-p [2] tt< if (alpha>0&lambda>0) tt<--*log (alpha)-*alpha* log (lambda)+ (-alpha)*sum (log (x)) if (alpha>0&lambda>0) tt<-tt+ (lambda**alpha)* sum (x**alpha) retur (tt)} est<-lm (f,p=c (,),iterlim=000) #the maximum likelihood estimates of alpha & lambda retured alpha<-est$estimate [] lambda<-est$estimate [2] The maximum likelihood estimates of the parameters as well as the egative logarithm of the maximized likelihood (NLLH) are give i Table 3 for the eight distributios fitted. The goodess of the fitted models was checked by meas of probability plots. A probability plot cosists of plots of the observed probabilities agaist the probabilities predicted by the fitted model. For example, for the stard Weibull ˆ model, ˆ exp{ ( λx() i ) } was plotted versus (i 0.375)/( +0.25), i =, 2,..., (as recommeded by Blom [27] Chambers et al. [28]), where x (i) are the sorted values of the observed fracture toughess. ˆ For the iverse Weibull model, exp{ ( x ˆ () i / λ) } was plotted versus (i 0.375)/(+ 0.25), i =, 2,...,. A objective measure of the goodess of fit was calculated by takig the sum of the absolute differeces betwee the observed probabilities the probabilities predicted by the fitted model. The values of this measure are show i Table 4. Note that five of the fitted distributios have three parameters while the other three distributios have two parameters. Although ot all of the distributios are ested, those with the same umber of parameters ca be compared by meas of the stard likelihood ratio test. It follows that the best fits are exhibited by the bottom four models: distributio, expoetiated Weibull distributio, Xie et al. s Weibull distributio distributio. This is uderstable because these distributios have more parameters, more recetly developed more flexible tha the other Weibull distributios. There is o evidece to suggest that certai models perform better for the toughest materials or the lightest materials (see Table 2). It is just that the more flexible models perform better irrespective of the stregth of the materials. These observatios are cofirmed by the values of the goodess of fit measure i Table Coclusios We have reviewed over 20 kow variatios of the Weibull distributio which could be used as possible models for material stregth. We have discussed the appropriateess of these distributios as models for brittle versus ductile stregth. We have also provided a compariso study based o six data sets o fracture toughess. We believe that this review will serve as a importat referece, help to provide better modelig ecourage developmets of further variatios of the Weibull distributio. Ackowledgmets The authors would like to thak the editor the three referees for carefully readig the paper for their commets which greatly improved the paper.
8 254 S. Nadarajah S. Kotz / Joural of Mechaical Sciece Techology 22 (2008) 247~254 Refereces [] A. C. Cohe, The reflected Weibull distributio. Techometrics, 5 (973) [2] N. Balakrisha S. Kocherlakota, O the double Weibull distributio: order statistics estimatio. Sakhyā, 47 (985) [3] J. S. White, The momets of log-weibull order statistics. Techometrics, (969) [4] A. Drapella, Complemetary Weibull distributio: ukow or just forgotto. Quality Reliability Egieerig Iteratioal, 9 (993) [5] G. S. Mudholkar G. D. Kollia, Geeralized Weibull family: a structural aalysis. Commuicatios i Statistics Theory Methods, 23 (994) [6] R. P. McEwe B. R. Parresol, Momet expressios summary statistics for the complete trucated Weibull distributio. Commuicatios i Statistics Theory Methods, 20 (99) [7] A. W. Marshall I. Olki, A ew method for addig a parameter to a family of distributios with applicatio to the expoetial Weibull families. Biometrika, 84 (997) [8] V. G. Voda, New models i durability tool-testig: pseudo-weibull distributio. Kyberetika, 25 (989) [9] E. W. Stacy, A geeralizatio of gamma distributio. Aals of Mathematical Statistics, 33 (962) [0] M. E. Ghitay, O a recet geeralizatio of a gamma distributio. Commuicatios i Statistics Theory Methods, 27 (998) [] G. S. Mudholkar, D. K. Srivastava M. Freimer, The expoetiated Weibull family. Techometrics, 37 (995) [2] G. S. Mudholkar A. D. Husto, The expoetiated Weibull family: some properties a flood data applicatio. Commuicatios i Statistics Theory Methods, 25 (996) [3] M. M. Nassar F. H. Eissa, O the expoetiated Weibull distributio. Commuicatios i Statistics Theory Methods, 32 (2003) [4] S. Nadarajah A. K. Gupta, O the momets of the expoetiatedweibull distributio. Commuicatios i Statistics Theory Methods, 34 (2005) [5] M. Xie, Y. Tag T. N. Goh, A modified Weibull extesio with bathtub-shaped failure rate fuctio. Reliability Egieerig & System Safety, 76 (2002) [6] Z. Che, A ew two-parameter lifetime distributio with bathtub shape or icreasig failure rate fuctio. Statistics Probability Letters, 49 (2000) [7] Y. Tag, M. Xie T. N. Goh, Statistical aalysis of a Weibull extesio model. Commuicatios I Statistics Theory Methods, 32 (2003) [8] J. W. Wu, H. L. Lu, C. H. Che, C. H. Wu, Statistical iferece about the shape parameter of the ew two-parameter bathtub-shaped lifetime distributio. Quality Reliability Egieerig Iteratioal, 20 (2004) [9] S. Nadarajah, O the momets of the modified- Weibull distributio. Reliability Egieerig System Safety, 90 (2005) 4-7. [20] C. D. Lai, M. Xie D. N. P. Murthy, Modified Weibull model. IEEE Trasactios o Reliability, 52 (2003) [2] G. S. Mudholkar D. K. Srivastava, Expoetiated Weibull family aalyzig bathtub failure-rate data. IEEE Trasactios o Reliability, 42 (993) [22] K. K. Phai, A ew modifed Weibull distributio. Commuicatios of the America Ceramic Society, 70 (987) [23] J. A. Kies, The stregth of glass. Naval Research Lab Report No 5093, Washigto DC, (958). [24] J. E. Deis R. B. Schabel, Numerical Methods for Ucostraied Optimizatio Noliear Equatios. Pretice-Hall, Eglewood Cliffs, New Jersey, (983). [25] R. B. Schabel, J. E. Kootz B. E. Weiss, A modular system of algorithms for ucostraied miimizatio. ACM Trasactios o Mathematical Software, (985) [26] R. Ihaka R. Getlema, R: A laguage for data aalysis graphics. Joural of Computatioal Graphical Statistics, 5 (996) [27] G. Blom, Statistical Estimates Trasformed Beta-variables. Joh Wiley Sos, New York, (958). [28] J. Chambers, W. Clevel, B. Kleier P. Tukey, Graphical Methods for Data Aalysis. Chapma Hall, (983).
ANOTHER WEIGHTED WEIBULL DISTRIBUTION FROM AZZALINI S FAMILY
ANOTHER WEIGHTED WEIBULL DISTRIBUTION FROM AZZALINI S FAMILY Sulema Nasiru, MSc. Departmet of Statistics, Faculty of Mathematical Scieces, Uiversity for Developmet Studies, Navrogo, Upper East Regio, Ghaa,
More informationConfidence interval for the two-parameter exponentiated Gumbel distribution based on record values
Iteratioal Joural of Applied Operatioal Research Vol. 4 No. 1 pp. 61-68 Witer 2014 Joural homepage: www.ijorlu.ir Cofidece iterval for the two-parameter expoetiated Gumbel distributio based o record values
More informationGoodness-Of-Fit For The Generalized Exponential Distribution. Abstract
Goodess-Of-Fit For The Geeralized Expoetial Distributio By Amal S. Hassa stitute of Statistical Studies & Research Cairo Uiversity Abstract Recetly a ew distributio called geeralized expoetial or expoetiated
More informationBayesian and E- Bayesian Method of Estimation of Parameter of Rayleigh Distribution- A Bayesian Approach under Linex Loss Function
Iteratioal Joural of Statistics ad Systems ISSN 973-2675 Volume 12, Number 4 (217), pp. 791-796 Research Idia Publicatios http://www.ripublicatio.com Bayesia ad E- Bayesia Method of Estimatio of Parameter
More informationMOMENT-METHOD ESTIMATION BASED ON CENSORED SAMPLE
Vol. 8 o. Joural of Systems Sciece ad Complexity Apr., 5 MOMET-METHOD ESTIMATIO BASED O CESORED SAMPLE I Zhogxi Departmet of Mathematics, East Chia Uiversity of Sciece ad Techology, Shaghai 37, Chia. Email:
More informationMaximum likelihood estimation from record-breaking data for the generalized Pareto distribution
METRON - Iteratioal Joural of Statistics 004, vol. LXII,. 3, pp. 377-389 NAGI S. ABD-EL-HAKIM KHALAF S. SULTAN Maximum likelihood estimatio from record-breakig data for the geeralized Pareto distributio
More informationA New Lifetime Distribution For Series System: Model, Properties and Application
Joural of Moder Applied Statistical Methods Volume 7 Issue Article 3 08 A New Lifetime Distributio For Series System: Model, Properties ad Applicatio Adil Rashid Uiversity of Kashmir, Sriagar, Idia, adilstat@gmail.com
More informationMathematical Modeling of Optimum 3 Step Stress Accelerated Life Testing for Generalized Pareto Distribution
America Joural of Theoretical ad Applied Statistics 05; 4(: 6-69 Published olie May 8, 05 (http://www.sciecepublishiggroup.com/j/ajtas doi: 0.648/j.ajtas.05040. ISSN: 6-8999 (Prit; ISSN: 6-9006 (Olie Mathematical
More informationADVANCED SOFTWARE ENGINEERING
ADVANCED SOFTWARE ENGINEERING COMP 3705 Exercise Usage-based Testig ad Reliability Versio 1.0-040406 Departmet of Computer Ssciece Sada Narayaappa, Aeliese Adrews Versio 1.1-050405 Departmet of Commuicatio
More informationProbability and statistics: basic terms
Probability ad statistics: basic terms M. Veeraraghava August 203 A radom variable is a rule that assigs a umerical value to each possible outcome of a experimet. Outcomes of a experimet form the sample
More informationDouble Stage Shrinkage Estimator of Two Parameters. Generalized Exponential Distribution
Iteratioal Mathematical Forum, Vol., 3, o. 3, 3-53 HIKARI Ltd, www.m-hikari.com http://dx.doi.org/.9/imf.3.335 Double Stage Shrikage Estimator of Two Parameters Geeralized Expoetial Distributio Alaa M.
More informationThe new class of Kummer beta generalized distributions
The ew class of Kummer beta geeralized distributios Rodrigo Rossetto Pescim 12 Clarice Garcia Borges Demétrio 1 Gauss Moutiho Cordeiro 3 Saralees Nadarajah 4 Edwi Moisés Marcos Ortega 1 1 Itroductio Geeralized
More informationDECOMPOSITION METHOD FOR SOLVING A SYSTEM OF THIRD-ORDER BOUNDARY VALUE PROBLEMS. Park Road, Islamabad, Pakistan
Mathematical ad Computatioal Applicatios, Vol. 9, No. 3, pp. 30-40, 04 DECOMPOSITION METHOD FOR SOLVING A SYSTEM OF THIRD-ORDER BOUNDARY VALUE PROBLEMS Muhammad Aslam Noor, Khalida Iayat Noor ad Asif Waheed
More informationGoodness-Of-Fit For The Generalized Exponential Distribution. Abstract
Goodess-Of-Fit For The Geeralized Expoetial Distributio By Amal S. Hassa stitute of Statistical Studies & Research Cairo Uiversity Abstract Recetly a ew distributio called geeralized expoetial or expoetiated
More informationBootstrap Intervals of the Parameters of Lognormal Distribution Using Power Rule Model and Accelerated Life Tests
Joural of Moder Applied Statistical Methods Volume 5 Issue Article --5 Bootstrap Itervals of the Parameters of Logormal Distributio Usig Power Rule Model ad Accelerated Life Tests Mohammed Al-Ha Ebrahem
More informationApproximate Confidence Interval for the Reciprocal of a Normal Mean with a Known Coefficient of Variation
Metodološki zvezki, Vol. 13, No., 016, 117-130 Approximate Cofidece Iterval for the Reciprocal of a Normal Mea with a Kow Coefficiet of Variatio Wararit Paichkitkosolkul 1 Abstract A approximate cofidece
More informationSome New Iterative Methods for Solving Nonlinear Equations
World Applied Scieces Joural 0 (6): 870-874, 01 ISSN 1818-495 IDOSI Publicatios, 01 DOI: 10.589/idosi.wasj.01.0.06.830 Some New Iterative Methods for Solvig Noliear Equatios Muhammad Aslam Noor, Khalida
More informationA Generalized Gamma-Weibull Distribution: Model, Properties and Applications
Marquette Uiversity e-publicatios@marquette Mathematics, Statistics ad Computer Sciece Faculty Research ad Publicatios Mathematics, Statistics ad Computer Sciece, Departmet of --06 A Geeralized Gamma-Weibull
More informationMinimax Estimation of the Parameter of Maxwell Distribution Under Different Loss Functions
America Joural of heoretical ad Applied Statistics 6; 5(4): -7 http://www.sciecepublishiggroup.com/j/ajtas doi:.648/j.ajtas.654.6 ISSN: 6-8999 (Prit); ISSN: 6-96 (Olie) Miimax Estimatio of the Parameter
More informationChapter 6 Sampling Distributions
Chapter 6 Samplig Distributios 1 I most experimets, we have more tha oe measuremet for ay give variable, each measuremet beig associated with oe radomly selected a member of a populatio. Hece we eed to
More informationCEE 522 Autumn Uncertainty Concepts for Geotechnical Engineering
CEE 5 Autum 005 Ucertaity Cocepts for Geotechical Egieerig Basic Termiology Set A set is a collectio of (mutually exclusive) objects or evets. The sample space is the (collectively exhaustive) collectio
More informationRecord Values from T-X Family of. Pareto-Exponential Distribution with. Properties and Simulations
Applied Mathematical Scieces, Vol. 3, 209, o., 33-44 HIKARI Ltd, www.m-hikari.com https://doi.org/0.2988/ams.209.879 Record Values from T-X Family of Pareto-Epoetial Distributio with Properties ad Simulatios
More informationEstimation of Gumbel Parameters under Ranked Set Sampling
Joural of Moder Applied Statistical Methods Volume 13 Issue 2 Article 11-2014 Estimatio of Gumbel Parameters uder Raked Set Samplig Omar M. Yousef Al Balqa' Applied Uiversity, Zarqa, Jorda, abuyaza_o@yahoo.com
More informationSequences of Definite Integrals, Factorials and Double Factorials
47 6 Joural of Iteger Sequeces, Vol. 8 (5), Article 5.4.6 Sequeces of Defiite Itegrals, Factorials ad Double Factorials Thierry Daa-Picard Departmet of Applied Mathematics Jerusalem College of Techology
More informationPAijpam.eu ON TENSOR PRODUCT DECOMPOSITION
Iteratioal Joural of Pure ad Applied Mathematics Volume 103 No 3 2015, 537-545 ISSN: 1311-8080 (prited versio); ISSN: 1314-3395 (o-lie versio) url: http://wwwijpameu doi: http://dxdoiorg/1012732/ijpamv103i314
More informationPOWER AKASH DISTRIBUTION AND ITS APPLICATION
POWER AKASH DISTRIBUTION AND ITS APPLICATION Rama SHANKER PhD, Uiversity Professor, Departmet of Statistics, College of Sciece, Eritrea Istitute of Techology, Asmara, Eritrea E-mail: shakerrama009@gmail.com
More informationR. van Zyl 1, A.J. van der Merwe 2. Quintiles International, University of the Free State
Bayesia Cotrol Charts for the Two-parameter Expoetial Distributio if the Locatio Parameter Ca Take o Ay Value Betwee Mius Iity ad Plus Iity R. va Zyl, A.J. va der Merwe 2 Quitiles Iteratioal, ruaavz@gmail.com
More informationBayesian Control Charts for the Two-parameter Exponential Distribution
Bayesia Cotrol Charts for the Two-parameter Expoetial Distributio R. va Zyl, A.J. va der Merwe 2 Quitiles Iteratioal, ruaavz@gmail.com 2 Uiversity of the Free State Abstract By usig data that are the mileages
More informationAccess to the published version may require journal subscription. Published with permission from: Elsevier.
This is a author produced versio of a paper published i Statistics ad Probability Letters. This paper has bee peer-reviewed, it does ot iclude the joural pagiatio. Citatio for the published paper: Forkma,
More informationG. R. Pasha Department of Statistics Bahauddin Zakariya University Multan, Pakistan
Deviatio of the Variaces of Classical Estimators ad Negative Iteger Momet Estimator from Miimum Variace Boud with Referece to Maxwell Distributio G. R. Pasha Departmet of Statistics Bahauddi Zakariya Uiversity
More informationGUIDE FOR THE USE OF THE DECISION SUPPORT SYSTEM (DSS)*
GUIDE FOR THE USE OF THE DECISION SUPPORT SYSTEM (DSS)* *Note: I Frech SAD (Système d Aide à la Décisio) 1. Itroductio to the DSS Eightee statistical distributios are available i HYFRAN-PLUS software to
More informationOnline Appendix to Accompany Further Improvements on Base-Stock Approximations for Independent Stochastic Lead Times with Order Crossover
10.187/msom.1070.0160 Olie Appedix to Accompay Further Improvemets o Base-Stock Approximatios for Idepedet Stochastic Lead Times with Order Crossover Lawrece W. Robiso Johso Graduate School of Maagemet
More informationConfidence Interval for Standard Deviation of Normal Distribution with Known Coefficients of Variation
Cofidece Iterval for tadard Deviatio of Normal Distributio with Kow Coefficiets of Variatio uparat Niwitpog Departmet of Applied tatistics, Faculty of Applied ciece Kig Mogkut s Uiversity of Techology
More informationThe (P-A-L) Generalized Exponential Distribution: Properties and Estimation
Iteratioal Mathematical Forum, Vol. 12, 2017, o. 1, 27-37 HIKARI Ltd, www.m-hikari.com https://doi.org/10.12988/imf.2017.610140 The (P-A-L) Geeralized Expoetial Distributio: Properties ad Estimatio M.R.
More informationThe New Probability Distribution: An Aspect to a Life Time Distribution
Math. Sci. Lett. 6, No. 1, 35-4 017) 35 Mathematical Sciece Letters A Iteratioal Joural http://dx.doi.org/10.18576/msl/060106 The New Probability Distributio: A Aspect to a Life Time Distributio Diesh
More informationNEW FAST CONVERGENT SEQUENCES OF EULER-MASCHERONI TYPE
UPB Sci Bull, Series A, Vol 79, Iss, 207 ISSN 22-7027 NEW FAST CONVERGENT SEQUENCES OF EULER-MASCHERONI TYPE Gabriel Bercu We itroduce two ew sequeces of Euler-Mascheroi type which have fast covergece
More informationExponential Families and Bayesian Inference
Computer Visio Expoetial Families ad Bayesia Iferece Lecture Expoetial Families A expoetial family of distributios is a d-parameter family f(x; havig the followig form: f(x; = h(xe g(t T (x B(, (. where
More informationA Note On The Exponential Of A Matrix Whose Elements Are All 1
Applied Mathematics E-Notes, 8(208), 92-99 c ISSN 607-250 Available free at mirror sites of http://wwwmaththuedutw/ ame/ A Note O The Expoetial Of A Matrix Whose Elemets Are All Reza Farhadia Received
More informationNumerical Conformal Mapping via a Fredholm Integral Equation using Fourier Method ABSTRACT INTRODUCTION
alaysia Joural of athematical Scieces 3(1): 83-93 (9) umerical Coformal appig via a Fredholm Itegral Equatio usig Fourier ethod 1 Ali Hassa ohamed urid ad Teh Yua Yig 1, Departmet of athematics, Faculty
More informationCHAPTER 4 BIVARIATE DISTRIBUTION EXTENSION
CHAPTER 4 BIVARIATE DISTRIBUTION EXTENSION 4. Itroductio Numerous bivariate discrete distributios have bee defied ad studied (see Mardia, 97 ad Kocherlakota ad Kocherlakota, 99) based o various methods
More informationThe Sampling Distribution of the Maximum. Likelihood Estimators for the Parameters of. Beta-Binomial Distribution
Iteratioal Mathematical Forum, Vol. 8, 2013, o. 26, 1263-1277 HIKARI Ltd, www.m-hikari.com http://d.doi.org/10.12988/imf.2013.3475 The Samplig Distributio of the Maimum Likelihood Estimators for the Parameters
More informationA proposed discrete distribution for the statistical modeling of
It. Statistical Ist.: Proc. 58th World Statistical Cogress, 0, Dubli (Sessio CPS047) p.5059 A proposed discrete distributio for the statistical modelig of Likert data Kidd, Marti Cetre for Statistical
More informationMATH 320: Probability and Statistics 9. Estimation and Testing of Parameters. Readings: Pruim, Chapter 4
MATH 30: Probability ad Statistics 9. Estimatio ad Testig of Parameters Estimatio ad Testig of Parameters We have bee dealig situatios i which we have full kowledge of the distributio of a radom variable.
More informationInvestigating the Significance of a Correlation Coefficient using Jackknife Estimates
Iteratioal Joural of Scieces: Basic ad Applied Research (IJSBAR) ISSN 2307-4531 (Prit & Olie) http://gssrr.org/idex.php?joural=jouralofbasicadapplied ---------------------------------------------------------------------------------------------------------------------------
More informationDepartment of Mathematics
Departmet of Mathematics Ma 3/103 KC Border Itroductio to Probability ad Statistics Witer 2017 Lecture 19: Estimatio II Relevat textbook passages: Larse Marx [1]: Sectios 5.2 5.7 19.1 The method of momets
More informationON POINTWISE BINOMIAL APPROXIMATION
Iteratioal Joural of Pure ad Applied Mathematics Volume 71 No. 1 2011, 57-66 ON POINTWISE BINOMIAL APPROXIMATION BY w-functions K. Teerapabolar 1, P. Wogkasem 2 Departmet of Mathematics Faculty of Sciece
More informationSTATISTICAL INFERENCE
STATISTICAL INFERENCE POPULATION AND SAMPLE Populatio = all elemets of iterest Characterized by a distributio F with some parameter θ Sample = the data X 1,..., X, selected subset of the populatio = sample
More informationDiscrete Orthogonal Moment Features Using Chebyshev Polynomials
Discrete Orthogoal Momet Features Usig Chebyshev Polyomials R. Mukuda, 1 S.H.Og ad P.A. Lee 3 1 Faculty of Iformatio Sciece ad Techology, Multimedia Uiversity 75450 Malacca, Malaysia. Istitute of Mathematical
More informationA Note on the Kolmogorov-Feller Weak Law of Large Numbers
Joural of Mathematical Research with Applicatios Mar., 015, Vol. 35, No., pp. 3 8 DOI:10.3770/j.iss:095-651.015.0.013 Http://jmre.dlut.edu.c A Note o the Kolmogorov-Feller Weak Law of Large Numbers Yachu
More informationChapter 6 Principles of Data Reduction
Chapter 6 for BST 695: Special Topics i Statistical Theory. Kui Zhag, 0 Chapter 6 Priciples of Data Reductio Sectio 6. Itroductio Goal: To summarize or reduce the data X, X,, X to get iformatio about a
More informationThe Riemann Zeta Function
Physics 6A Witer 6 The Riema Zeta Fuctio I this ote, I will sketch some of the mai properties of the Riema zeta fuctio, ζ(x). For x >, we defie ζ(x) =, x >. () x = For x, this sum diverges. However, we
More informationResearch Article A Unified Weight Formula for Calculating the Sample Variance from Weighted Successive Differences
Discrete Dyamics i Nature ad Society Article ID 210761 4 pages http://dxdoiorg/101155/2014/210761 Research Article A Uified Weight Formula for Calculatig the Sample Variace from Weighted Successive Differeces
More information1 6 = 1 6 = + Factorials and Euler s Gamma function
Royal Holloway Uiversity of Lodo Departmet of Physics Factorials ad Euler s Gamma fuctio Itroductio The is a self-cotaied part of the course dealig, essetially, with the factorial fuctio ad its geeralizatio
More informationEXAMINATIONS OF THE ROYAL STATISTICAL SOCIETY
EXAMINATIONS OF THE ROYAL STATISTICAL SOCIETY GRADUATE DIPLOMA, 016 MODULE : Statistical Iferece Time allowed: Three hours Cadidates should aswer FIVE questios. All questios carry equal marks. The umber
More informationA GENERALIZATION OF THE SYMMETRY BETWEEN COMPLETE AND ELEMENTARY SYMMETRIC FUNCTIONS. Mircea Merca
Idia J Pure Appl Math 45): 75-89 February 204 c Idia Natioal Sciece Academy A GENERALIZATION OF THE SYMMETRY BETWEEN COMPLETE AND ELEMENTARY SYMMETRIC FUNCTIONS Mircea Merca Departmet of Mathematics Uiversity
More informationEstimation of Population Mean Using Co-Efficient of Variation and Median of an Auxiliary Variable
Iteratioal Joural of Probability ad Statistics 01, 1(4: 111-118 DOI: 10.593/j.ijps.010104.04 Estimatio of Populatio Mea Usig Co-Efficiet of Variatio ad Media of a Auxiliary Variable J. Subramai *, G. Kumarapadiya
More informationApplied Mathematics Letters. On the properties of Lucas numbers with binomial coefficients
Applied Mathematics Letters 3 (1 68 7 Cotets lists available at ScieceDirect Applied Mathematics Letters joural homepage: wwwelseviercom/locate/aml O the properties of Lucas umbers with biomial coefficiets
More informationStat 319 Theory of Statistics (2) Exercises
Kig Saud Uiversity College of Sciece Statistics ad Operatios Research Departmet Stat 39 Theory of Statistics () Exercises Refereces:. Itroductio to Mathematical Statistics, Sixth Editio, by R. Hogg, J.
More informationCOMPLEX FACTORIZATIONS OF THE GENERALIZED FIBONACCI SEQUENCES {q n } Sang Pyo Jun
Korea J. Math. 23 2015) No. 3 pp. 371 377 http://dx.doi.org/10.11568/kjm.2015.23.3.371 COMPLEX FACTORIZATIONS OF THE GENERALIZED FIBONACCI SEQUENCES {q } Sag Pyo Ju Abstract. I this ote we cosider a geeralized
More informationOn Algorithm for the Minimum Spanning Trees Problem with Diameter Bounded Below
O Algorithm for the Miimum Spaig Trees Problem with Diameter Bouded Below Edward Kh. Gimadi 1,2, Alexey M. Istomi 1, ad Ekateria Yu. Shi 2 1 Sobolev Istitute of Mathematics, 4 Acad. Koptyug aveue, 630090
More informationResearch Article A New Second-Order Iteration Method for Solving Nonlinear Equations
Abstract ad Applied Aalysis Volume 2013, Article ID 487062, 4 pages http://dx.doi.org/10.1155/2013/487062 Research Article A New Secod-Order Iteratio Method for Solvig Noliear Equatios Shi Mi Kag, 1 Arif
More informationThis is an introductory course in Analysis of Variance and Design of Experiments.
1 Notes for M 384E, Wedesday, Jauary 21, 2009 (Please ote: I will ot pass out hard-copy class otes i future classes. If there are writte class otes, they will be posted o the web by the ight before class
More informationBasis for simulation techniques
Basis for simulatio techiques M. Veeraraghava, March 7, 004 Estimatio is based o a collectio of experimetal outcomes, x, x,, x, where each experimetal outcome is a value of a radom variable. x i. Defiitios
More informationExpectation and Variance of a random variable
Chapter 11 Expectatio ad Variace of a radom variable The aim of this lecture is to defie ad itroduce mathematical Expectatio ad variace of a fuctio of discrete & cotiuous radom variables ad the distributio
More informationReliability Measures of a Series System with Weibull Failure Laws
Iteratioal Joural of Statistics ad Systems ISSN 973-2675 Volume, Number 2 (26), pp. 73-86 Research Idia Publicatios http://www.ripublicatio.com Reliability Measures of a Series System with Weibull Failure
More informationEECS564 Estimation, Filtering, and Detection Hwk 2 Solns. Winter p θ (z) = (2θz + 1 θ), 0 z 1
EECS564 Estimatio, Filterig, ad Detectio Hwk 2 Sols. Witer 25 4. Let Z be a sigle observatio havig desity fuctio where. p (z) = (2z + ), z (a) Assumig that is a oradom parameter, fid ad plot the maximum
More informationModified Ratio Estimators Using Known Median and Co-Efficent of Kurtosis
America Joural of Mathematics ad Statistics 01, (4): 95-100 DOI: 10.593/j.ajms.01004.05 Modified Ratio s Usig Kow Media ad Co-Efficet of Kurtosis J.Subramai *, G.Kumarapadiya Departmet of Statistics, Podicherry
More informationComparison of Minimum Initial Capital with Investment and Non-investment Discrete Time Surplus Processes
The 22 d Aual Meetig i Mathematics (AMM 207) Departmet of Mathematics, Faculty of Sciece Chiag Mai Uiversity, Chiag Mai, Thailad Compariso of Miimum Iitial Capital with Ivestmet ad -ivestmet Discrete Time
More informationLecture 7: Properties of Random Samples
Lecture 7: Properties of Radom Samples 1 Cotiued From Last Class Theorem 1.1. Let X 1, X,...X be a radom sample from a populatio with mea µ ad variace σ
More informationMOST PEOPLE WOULD RATHER LIVE WITH A PROBLEM THEY CAN'T SOLVE, THAN ACCEPT A SOLUTION THEY CAN'T UNDERSTAND.
XI-1 (1074) MOST PEOPLE WOULD RATHER LIVE WITH A PROBLEM THEY CAN'T SOLVE, THAN ACCEPT A SOLUTION THEY CAN'T UNDERSTAND. R. E. D. WOOLSEY AND H. S. SWANSON XI-2 (1075) STATISTICAL DECISION MAKING Advaced
More informationThe standard deviation of the mean
Physics 6C Fall 20 The stadard deviatio of the mea These otes provide some clarificatio o the distictio betwee the stadard deviatio ad the stadard deviatio of the mea.. The sample mea ad variace Cosider
More informationResearch Article A Note on Ergodicity of Systems with the Asymptotic Average Shadowing Property
Discrete Dyamics i Nature ad Society Volume 2011, Article ID 360583, 6 pages doi:10.1155/2011/360583 Research Article A Note o Ergodicity of Systems with the Asymptotic Average Shadowig Property Risog
More informationPower Comparison of Some Goodness-of-fit Tests
Florida Iteratioal Uiversity FIU Digital Commos FIU Electroic Theses ad Dissertatios Uiversity Graduate School 7-6-2016 Power Compariso of Some Goodess-of-fit Tests Tiayi Liu tliu019@fiu.edu DOI: 10.25148/etd.FIDC000750
More informationBayesian Methods: Introduction to Multi-parameter Models
Bayesia Methods: Itroductio to Multi-parameter Models Parameter: θ = ( θ, θ) Give Likelihood p(y θ) ad prior p(θ ), the posterior p proportioal to p(y θ) x p(θ ) Margial posterior ( θ, θ y) is Iterested
More informationHarmonic Number Identities Via Euler s Transform
1 2 3 47 6 23 11 Joural of Iteger Sequeces, Vol. 12 2009), Article 09.6.1 Harmoic Number Idetities Via Euler s Trasform Khristo N. Boyadzhiev Departmet of Mathematics Ohio Norther Uiversity Ada, Ohio 45810
More informationAbstract. Ranked set sampling, auxiliary variable, variance.
Hacettepe Joural of Mathematics ad Statistics Volume (), 1 A class of Hartley-Ross type Ubiased estimators for Populatio Mea usig Raked Set Samplig Lakhkar Kha ad Javid Shabbir Abstract I this paper, we
More informationChimica Inorganica 3
himica Iorgaica Irreducible Represetatios ad haracter Tables Rather tha usig geometrical operatios, it is ofte much more coveiet to employ a ew set of group elemets which are matrices ad to make the rule
More informationSHARP INEQUALITIES INVOLVING THE CONSTANT e AND THE SEQUENCE (1 + 1/n) n
SHARP INEQUALITIES INVOLVING THE CONSTANT e AND THE SEQUENCE + / NECDET BATIR Abstract. Several ew ad sharp iequalities ivolvig the costat e ad the sequece + / are proved.. INTRODUCTION The costat e or
More information[412] A TEST FOR HOMOGENEITY OF THE MARGINAL DISTRIBUTIONS IN A TWO-WAY CLASSIFICATION
[412] A TEST FOR HOMOGENEITY OF THE MARGINAL DISTRIBUTIONS IN A TWO-WAY CLASSIFICATION BY ALAN STUART Divisio of Research Techiques, Lodo School of Ecoomics 1. INTRODUCTION There are several circumstaces
More informationMultivariate Analysis of Variance Using a Kotz Type Distribution
Proceedigs of the World Cogress o Egieerig 2008 Vol II WCE 2008, July 2-4, 2008, Lodo, UK Multivariate Aalysis of Variace Usig a Kotz Type Distributio Kusaya Plugpogpu, ad Dayaad N Naik Abstract Most stadard
More informationGoodness-of-Fit Tests and Categorical Data Analysis (Devore Chapter Fourteen)
Goodess-of-Fit Tests ad Categorical Data Aalysis (Devore Chapter Fourtee) MATH-252-01: Probability ad Statistics II Sprig 2019 Cotets 1 Chi-Squared Tests with Kow Probabilities 1 1.1 Chi-Squared Testig................
More informationON BARTLETT CORRECTABILITY OF EMPIRICAL LIKELIHOOD IN GENERALIZED POWER DIVERGENCE FAMILY. Lorenzo Camponovo and Taisuke Otsu.
ON BARTLETT CORRECTABILITY OF EMPIRICAL LIKELIHOOD IN GENERALIZED POWER DIVERGENCE FAMILY By Lorezo Campoovo ad Taisuke Otsu October 011 COWLES FOUNDATION DISCUSSION PAPER NO. 185 COWLES FOUNDATION FOR
More informationElement sampling: Part 2
Chapter 4 Elemet samplig: Part 2 4.1 Itroductio We ow cosider uequal probability samplig desigs which is very popular i practice. I the uequal probability samplig, we ca improve the efficiecy of the resultig
More informationComparison Study of Series Approximation. and Convergence between Chebyshev. and Legendre Series
Applied Mathematical Scieces, Vol. 7, 03, o. 6, 3-337 HIKARI Ltd, www.m-hikari.com http://d.doi.org/0.988/ams.03.3430 Compariso Study of Series Approimatio ad Covergece betwee Chebyshev ad Legedre Series
More informationHigher-order iterative methods by using Householder's method for solving certain nonlinear equations
Math Sci Lett, No, 7- ( 7 Mathematical Sciece Letters A Iteratioal Joural http://dxdoiorg/785/msl/5 Higher-order iterative methods by usig Householder's method for solvig certai oliear equatios Waseem
More informationSelf-normalized deviation inequalities with application to t-statistic
Self-ormalized deviatio iequalities with applicatio to t-statistic Xiequa Fa Ceter for Applied Mathematics, Tiaji Uiversity, 30007 Tiaji, Chia Abstract Let ξ i i 1 be a sequece of idepedet ad symmetric
More informationApproximations to the Distribution of the Sample Correlation Coefficient
World Academy of Sciece Egieerig ad Techology Iteratioal Joural of Mathematical ad Computatioal Scieces Vol:5 No:4 0 Approximatios to the Distributio of the Sample Correlatio Coefficiet Joh N Haddad ad
More informationGeneralization of Samuelson s inequality and location of eigenvalues
Proc. Idia Acad. Sci. Math. Sci.) Vol. 5, No., February 05, pp. 03. c Idia Academy of Scieces Geeralizatio of Samuelso s iequality ad locatio of eigevalues R SHARMA ad R SAINI Departmet of Mathematics,
More informationA GRÜSS TYPE INEQUALITY FOR SEQUENCES OF VECTORS IN NORMED LINEAR SPACES AND APPLICATIONS
A GRÜSS TYPE INEQUALITY FOR SEQUENCES OF VECTORS IN NORMED LINEAR SPACES AND APPLICATIONS S. S. DRAGOMIR Abstract. A discrete iequality of Grüss type i ormed liear spaces ad applicatios for the discrete
More informationAsymptotic distribution of products of sums of independent random variables
Proc. Idia Acad. Sci. Math. Sci. Vol. 3, No., May 03, pp. 83 9. c Idia Academy of Scieces Asymptotic distributio of products of sums of idepedet radom variables YANLING WANG, SUXIA YAO ad HONGXIA DU ollege
More informationDimension-free PAC-Bayesian bounds for the estimation of the mean of a random vector
Dimesio-free PAC-Bayesia bouds for the estimatio of the mea of a radom vector Olivier Catoi CREST CNRS UMR 9194 Uiversité Paris Saclay olivier.catoi@esae.fr Ilaria Giulii Laboratoire de Probabilités et
More informationLecture 19: Convergence
Lecture 19: Covergece Asymptotic approach I statistical aalysis or iferece, a key to the success of fidig a good procedure is beig able to fid some momets ad/or distributios of various statistics. I may
More informationEXPANSION FORMULAS FOR APOSTOL TYPE Q-APPELL POLYNOMIALS, AND THEIR SPECIAL CASES
LE MATEMATICHE Vol. LXXIII 208 Fasc. I, pp. 3 24 doi: 0.448/208.73.. EXPANSION FORMULAS FOR APOSTOL TYPE Q-APPELL POLYNOMIALS, AND THEIR SPECIAL CASES THOMAS ERNST We preset idetities of various kids for
More informationREGRESSION WITH QUADRATIC LOSS
REGRESSION WITH QUADRATIC LOSS MAXIM RAGINSKY Regressio with quadratic loss is aother basic problem studied i statistical learig theory. We have a radom couple Z = X, Y ), where, as before, X is a R d
More informationProperties and Hypothesis Testing
Chapter 3 Properties ad Hypothesis Testig 3.1 Types of data The regressio techiques developed i previous chapters ca be applied to three differet kids of data. 1. Cross-sectioal data. 2. Time series data.
More informationChapter 13, Part A Analysis of Variance and Experimental Design
Slides Prepared by JOHN S. LOUCKS St. Edward s Uiversity Slide 1 Chapter 13, Part A Aalysis of Variace ad Eperimetal Desig Itroductio to Aalysis of Variace Aalysis of Variace: Testig for the Equality of
More informationResampling Methods. X (1/2), i.e., Pr (X i m) = 1/2. We order the data: X (1) X (2) X (n). Define the sample median: ( n.
Jauary 1, 2019 Resamplig Methods Motivatio We have so may estimators with the property θ θ d N 0, σ 2 We ca also write θ a N θ, σ 2 /, where a meas approximately distributed as Oce we have a cosistet estimator
More informationLecture 6 Chi Square Distribution (χ 2 ) and Least Squares Fitting
Lecture 6 Chi Square Distributio (χ ) ad Least Squares Fittig Chi Square Distributio (χ ) Suppose: We have a set of measuremets {x 1, x, x }. We kow the true value of each x i (x t1, x t, x t ). We would
More informationNUMERICAL METHOD FOR SINGULARLY PERTURBED DELAY PARABOLIC PARTIAL DIFFERENTIAL EQUATIONS
THERMAL SCIENCE, Year 07, Vol., No. 4, pp. 595-599 595 NUMERICAL METHOD FOR SINGULARLY PERTURBED DELAY PARABOLIC PARTIAL DIFFERENTIAL EQUATIONS by Yula WANG *, Da TIAN, ad Zhiyua LI Departmet of Mathematics,
More informationBayesian inference for Parameter and Reliability function of Inverse Rayleigh Distribution Under Modified Squared Error Loss Function
Australia Joural of Basic ad Applied Scieces, (6) November 26, Pages: 24-248 AUSTRALIAN JOURNAL OF BASIC AND APPLIED SCIENCES ISSN:99-878 EISSN: 239-844 Joural home page: www.ajbasweb.com Bayesia iferece
More information