Commonly Used Distributions and Parameter Estimation
|
|
- Merry Mills
- 5 years ago
- Views:
Transcription
1 Commoly Use Distributios a Parameter stimatio Berli Che Departmet of Computer Sciece & Iformatio gieerig Natioal Taiwa Normal Uiversity Referece:. W. Navii. Statistics for gieerig a Scietists. Chapter 4 & Teachig Material
2 How to stimate Populatio (Distributio) Parameters? Populatio Sample Iferece Parameters Statistics - Ubiase stimate? - stimatio Ucertaity? Statistics-Berli Che
3 The Beroulli Distributio We use the Beroulli istributio whe we have a experimet which ca result i oe of two outcomes Oe outcome is labele success, a the other outcome is labele l failure The probability of a success is eote by p. The probability of a failure is the p Such a trial is calle a Beroulli trial with success probability p Statistics-Berli Che 3
4 xamples. The simplest Beroulli trial is the toss of a coi. The two outcomes are heas a tails. If we efie heas to be the success outcome, the p is the probability that the coi comes up heas. For a fair coi, p = ½. Aother Beroulli trial is a selectio of a compoet from a populatio of compoets, some of which are efective. If we efie success to be a efective compoet, the p is the proportio of efective compoets i the populatiop Statistics-Berli Che 4
5 ~ Beroulli(p) For ay Beroulli trial, we efie a raom variable as follows: If the experimet results i a success, the =. Otherwise, = 0. It follows that t is a iscrete raom variable, with probability mass fuctio p(x) efie by p(0) = P( = 0) = p p() = P( = ) = p p(x) = 0 for ay value of x other tha 0 or Statistics-Berli Che 5
6 Mea a Variace of Beroulli If ~ Beroulli(p), the = 0(- p) + (p) = p (0 p)( p) ( p)( p) p( p) Statistics-Berli Che 6
7 The Biomial Distributio If a total of Beroulli trials are coucte, a The trials are iepeet ach trial has the same success probability p is the umber of successes i the trials The has the biomial istributio with parameters a p, eote ~ Bi(,p) Probability Histogram Bi(0, 0.4) Bi(0, 0.) Statistics-Berli Che 7
8 Aother Use of the Biomial Assume that a fiite populatio p cotais items of two types, successes a failures, a that a simple raom sample is raw from the populatio. The if the sample size is o more tha 5% of the populatio, the biomial i istributio may be use to moel the umber of successes Sample items ca be therefore assume to be iepeet of each other ach sample item is a Beroulli trial Statistics-Berli Che 8
9 pmf, Mea a Variace of Biomial If ~ Bi(,,p), the probability mass fuctio of is!! x x p ( p), x 0,,..., px ( ) P ( x) x!( x)! 0, otherwise Mea: = p Variace: p( p) x! x! x! Statistics-Berli Che 9
10 More o the Biomial Assume iepeet Beroulli trials are coucte ach trial has probability bilit of success p Let Y,, Y be efie as follows: Y i = if the i th trial results i success, a Y i = 0 otherwise (ach of the Y i has the Beroulli(p) istributio) Now, let represet the umber of successes amog the trials. So, = Y + + Y This shows that a biomial raom variable ca be expresse as a sum of Beroulli raom variables Samplig a sigle value from a Bi(, p) populatio is equivalet to rawig a sample of size from a Beroulli(p) with populatio, a the summig the sample value Statistics-Berli Che 0
11 stimate of p If ~ Bi(, p), the the sample proportio pˆ / umber of successes Y ˆ Y Y p umber of trials ( is use to estimate the success probability p Note: Bias is the ifferece p p. ˆp p is ubiase p ˆ ˆ 0 The ucertaity i ˆp is pˆ Y Y Y p I practice, whe computig, we substitute for p, sice p is ukow Refer to xample 4.4 (p. 0) p ˆp ) Statistics-Berli Che
12 The Poisso Distributio Oe way to thik of the Poisso istributio is as a approximatio to the biomial istributio whe is large a p is small It is the case whe is large a p is small the mass fuctio epes almost etirely o the mea p, very little o the specific values of a p We ca therefore approximate the biomial mass fuctio with a quatity λ =p; this λ is the parameter i the Poisso istributio Statistics-Berli Che
13 pmf, Mea a Variace of Poisso If ~ Poisso(λ), the probability mass fuctio of is x e, for x = 0,,,... px ( ) P ( x ) x! 0, otherwise Probability Histogram Mea: = λ Variace: Poisso() Poisso(0) Note: must be a iscrete raom variable a λ must be a positive costat Statistics-Berli Che 3
14 Relatioship betwee Biomial a Poisso The Poisso PMF with parameter is a goo approximatio for a biomial PMF with parameters approximatio for a biomial PMF with parameters a, provie that, is very large a is very small p p p λ is very small k k λ p p k! lim k k k k λ λ k k λ p p λ p p k k! lim ) (!!! lim k k k k k λ k k λ k! lim! λ k x k k e k λ e x λ λ k k λ! lim ) lim (! lim Statistics-Berli Che 4 Refer to xamples 4.7, 4.9 a 4.0 (p. 9 & p. 0) k!
15 Poisso Distributio to stimate Rate Let λ eote the mea umber of evets that occur i oe uit of time or space. Let eote the umber of evets that are observe to occur i t uits of time or space If ~ Poisso(λt), we estimate λ with ˆ t Note: ˆ ˆ t t t t is ubiase ( ˆ ) ˆ The ucertaity i is ˆ t t t t I practice, we substitute ˆ for λ, sice λ is ukow t Statistics-Berli Che 5
16 Some Other Discrete Distributios Cosier a fiite populatio cotaiig two types of items, which may be calle successes a failures A simple raom sample is raw from the populatio ach item sample costitutes a Beroulli trial As each item is selecte, the probability of successes i the remaiig populatio ecreases or icreases, epeig o whether the sample item was a success or a failure For this reaso the trials are ot iepeet, so the umber of successes i the sample oes ot follow a biomial istributio The istributio that properly escribes the umber of successes is the hypergeometric istributio Statistics-Berli Che 6
17 pmf of Hypergeometric Assume a fiite populatio p cotais N items, of which R are classifie as successes a N R are classifie as failures Assume that items are sample from this populatio, a let represet the umber of successes i the sample The has a hypergeometric istributio with parameters N, R, a, which ca be eote ~ H(N,R,). The probability mass fuctio of is RN R x x, if max(0, R N) xmi(, R) px ( ) P ( x ) N 0, otherwise Statistics-Berli Che 7
18 Mea a Variace of Hypergeometric If ~ H(N,, R, ), the Mea of : R N Variace of : R R N N N N Statistics-Berli Che 8
19 Geometric Distributio Assume that a sequece of iepeet Beroulli trials is coucte, each with the same probability of success, p Let represet the umber of trials up to a icluig the first success The is a iscrete raom variable, which h is sai to have the geometric istributio with parameter p. We write ~ Geom(p). Statistics-Berli Che 9
20 pmf, Mea a Variace of Geometric If ~ Geom(p), the The pmf of is p p x px ( ) P ( x) 0, 0 otherwise x ( ),,,... The mea of is p The variace of is p p Statistics-Berli Che 0
21 Negative Biomial Distributio The egative biomial istributio is a extesio of the geometric istributio. Let r be a positive iteger. Assume that iepeet Beroulli trials, each with success probability bilit p, are coucte, a let eote the umber of trials up to a icluig the r th success The has the egative biomial istributio with parameters r a p. We write ~ NB(r,p) Note: If ~ NB(r,p), the = Y + + Y r where Y,,Y r are iepeet raom variables, each with Geom(p) )istributio tib ti 0,,, 0,,, 0,,,0,.., x trials i total y y y r Statistics-Berli Che
22 pmf, Mea a Variace of Negative Biomial If ~ NB(r,p), the The pmf of is x r xr p ( p), xr, r,... px ( ) P ( x) r 0, otherwise The mea of is r p The variace of is r ( p ) p Statistics-Berli Che
23 Multiomial Distributio A Beroulli trial is a process that results i oe of two possible outcomes. A geeralizatio of the Beroulli trial is the multiomial trial, which is a process that ca result i ay of k outcomes, where k. We eote the probabilities of the k outcomes by p,,p k (p + +p k =) Now assume that iepeet multiomial trials are coucte each with k possible outcomes a with the same probabilities p,,p k. Number the outcomes,,, k. For each outcome i, let i eote the umber of trials that t result i that t outcome. The,, k are iscrete raom variables. The collectio,, k is sai to have the multiomial istributio with parameters, p,,p k. We write,, k ~ MN(, p,,p k ) Statistics-Berli Che 3
24 pmf of Multiomial If,, k ~ MN(, p,,p k ), the the pmf of,, k is,, k (,p,,p k ), p,, k! k i x! x! x! k p( x) P( x) a x i 0, otherwise x x x p p p k, x 0,,,...,,,, Ca be viewe as a joit probability mass fuctio of,, k Note that if,, k ~ MN(, p,,p k ), the for each i, i ~ Bi(, p i ) Statistics-Berli Che 4
25 The Normal Distributio The ormal istributio (also calle the Gaussia istributio) is by far the most commoly use istributio i statistics. This istributio provies a goo moel for may, although h ot all, cotiuous populatios The ormal istributio is cotiuous rather tha iscrete. The mea of a ormal populatio may have ay value, a the variace may have ay positive value Statistics-Berli Che 5
26 pmf, Mea a Variace of Normal The probability esity fuctio of a ormal populatio p with mea a variace is give by ( x ) / f ( x) e, x If ~ N(, ), the the mea a variace of are give by Statistics-Berli Che 6
27 % Rule The above figure represets a plot of the ormal probability esity fuctio with mea a staar eviatio. Note that the curve is symmetric about, so that is the meia as well as the mea. It is also the case for the ormal populatio About 68% of the populatio is i the iterval About 95% of the populatio is i the iterval About 99.7% of the populatio is i the iterval 3 Statistics-Berli Che 7
28 Staar Uits The proportio p of a ormal populatio p that is withi a give umber of staar eviatios of the mea is the same for ay ormal populatio For this reaso, whe ealig with ormal populatios, we ofte covert from the uits i which the populatio items were origially measure to staar uits Staar uits tell how may staar eviatios a observatio is from the populatio mea Statistics-Berli Che 8
29 Staar Normal Distributio I geeral, we covert to staar uits by subtractig the mea a iviig by the staar eviatio. Thus, if x is a item sample from a ormal populatio with mea a variace, the staar uit equivalet of x is the umber z, where z = (x - )/ The umber z is sometimes calle the z-score of x. The z-score is a item sample from a ormal populatio with mea 0 a staar eviatio of. This ormal istributio is calle the staar ormal istributio Statistics-Berli Che 9
30 xamples. Q: Alumium sheets use to make beverage cas have thickesses that are ormally istribute with mea 0 a staar eviatio.3. A particular sheet is 0.8 thousaths of a ich thick. Fi the z-score: As.: z = (0.8 0)/.3 = 0.6. Q: Use the same iformatio as i. The thickess of a certai sheet has a z-score of -.7. Fi the thickess of the sheet i the origial uits of thousaths of iches: As.: -.7 = (x 0)/.3 x = -.7(.3) + 0 = 7.8 Statistics-Berli Che 30
31 Fiig Areas Uer the Normal Curve The proportio of a ormal populatio that lies withi a give iterval is equal to the area uer the ormal probability esity above that iterval. This woul suggest itegratig the ormal pf; this itegral have o close form solutio So, the areas uer the curve are approximate umerically a are available i Table A. (Z-table). This table provies area uer the curve for the staar ormal esity. We ca covert ay ormal ito a staar ormal so that we ca compute areas uer the curve The table gives the area i the left-ha tail of the curve Other areas ca be calculate l by subtractio ti or by usig the fact that the total area uer the curve is Statistics-Berli Che 3
32 Z-Table (/) Statistics-Berli Che 3
33 Z-Table (/) Statistics-Berli Che 33
34 xamples. Q: Fi the area uer ormal curve to the left of z = 0.47 As.: From the z table, the area is Q: Fi the area uer the curve to the right of z =.38 As.: From the z table, the area to the left of.38 is Therefore the area to the right is 0.96 = Statistics-Berli Che 34
35 More xamples. Q: Fi the area uer the ormal curve betwee z = 0.7 a z =8.8. As.: The area to the left of z =.8 is The area to the left of z = 0.7 is So the area betwee is = Q: What z-score correspos to the 75 th percetile of a ormal curve? As.: To aswer this questio, we use the z table i reverse. We ee to fi the z-score for which 75% of the area of curve is to the left. From the boy of the table, the closest area to 75% is , correspoig to a z-score of 0.67 Statistics-Berli Che 35
36 Liear Combiatios of Iepeet Normal RVs The liear combiatios of iepeet ormal raom variables are still ormal raom variables Let N,,, ~ N are iepeet, the Y Mea ~, c Variace c c c is ormal with Y c Y c We have to istiguish the meaig of from that of f y c f y c f Y y c c c i i Y Statistics-Berli Che 36
37 valuatig a stimator : Bias a Variace (/3) (/3) The mea square error of the estimator ca be further q ecompose ito two parts respectively compose of bias a variace, θ θ r (Mea Square rror, MS-- mea of the square error) θ θ θ θ θ θ θ θ costat costat θ θ θ 0 θ variace bias Statistics-Berli Che 37 Cf. Sectio 4.9 (cf. q a q i pp. 79)
38 valuatig a stimator : Bias a Variace (/3) (a ki of ucertaity) Statistics-Berli Che 38
39 valuatig a stimator : Bias a Variace (3/3) Bias a Variace: A xample x ifferet samples for a ukow populatio x, y F y x x x 3 y F x error of measuremet Statistics-Berli Che 39
40 stimatig the Parameters of Normal If,,,, are a raom sample from a N(, ) istributio, is estimate with the sample mea a is estimate with the sample variace s i i s i i ubiase estimator asymptotically ubiase estimator? As with ay sample mea, the ucertaity i which we replace with s/, if is ukow. The mea is a ubiase estimator of. is / Statistics-Berli Che 40
41 Sample Variace is a Asymptotically Ubiase stimator (/) Ubiase stimator (/) Sample variace is a asymptotically ubiase s p y p y estimator of the populatio variace s i i i i i i i s i i i i i i i i Statistics-Berli Che 4 i i
42 Sample Variace is a Asymptotically Ubiase stimator (/) Ubiase stimator (/) Var i i s Var Var i i i i i The size of the observe sample Statistics-Berli Che 4
43 The Logormal Distributio For ata that cotai outliers (o the right of the axis), the ormal istributio ib ti is geerally ot appropriate. The logormal istributio, which is relate to the ormal istributio, is ofte a goo choice for these ata sets If ~ N(, ), the the raom variable Y = e has the logormal istributio tio with parameters a If Y has the logormal istributio with parameters a, the the raom variable = lyy has the N(, ) istributio Probability Desity Fuctio a logormal istributio with parameters 0, Statistics-Berli Che 43
44 pf, Mea a Variace of Logormal The pf of a logormal raom variable with parameters a is f y y 0, exp l y Otherwise, y The mea (Y) ( ) a variace V(Y) ( ) are give by 0 Y ( ) e VY ( ) e e / Ca be show by avace methos Statistics-Berli Che 44
45 pf, Mea a Variace of Logormal Recall Derive Distributios exp, ~, x x f N e Y log log y F y x P y e P y Y P y F Y log log log y y y y F y y F y f Y Y log y y f log exp y y Statistics-Berli Che 45
46 Test of Logormality Trasform the ata by takig the atural logarithm (or ay logarithm) of each value Plot the histogram of the trasforme ata to etermie whether these logs come from a ormal populatio Probability Histogram takig the atural logarithm o the values of the ata Statistics-Berli Che 46
47 The xpoetial Distributio The expoetial istributio is a cotiuous istributio that is sometimes use to moel the time that elapses before a evet occurs Such a time is ofte calle a waitig time The probability esity of the expoetial istributio ivolves a parameter, which is a positive costat λ whose value etermies the esity fuctio s locatio a shape We write ~ xp(λ) Statistics-Berli Che 47
48 pf, cf, Mea a Variace of xpoetial The pf of a expoetial r.v. is x e, x 0 f( x). 0, otherwise The cf of a expoetial r.v. is 0, x 0 F( x). x e, x 0 The mea of a expoetial r.v. is /. The variace of a expoetial r.v. is /. Probability Desity Fuctio Statistics-Berli Che 48
49 Lack of Memory Property for xpoetial The expoetial istributio has a property kow as the p p p y lack of memory property: If T ~ xp(λ), a t a s are positive umbers, the P(T > t + s T > s) = P(T > t) s T P s T s t T P s T s t T P s F s t F s T P s t T P s t T T t T P t F e e e T t s s t Statistics-Berli Che 49
50 stimatig the Parameter of xpoetial If,, are a raom sample from xp(λ), the the parameter λ is estimate with ˆ /. This estimator is biase. This bias is approximately equal to λ/ (specifically, ˆ ). The ucertaity i ˆ is estimate with ˆ a ˆ This ucertaity estimate is reasoably goo whe the sample size is more tha 0 Statistics-Berli Che 50
51 The Gamma Distributio (/) Let s cosier the gamma fuctio For r > 0, the gamma fuctio is efie by r t r t e t 0 ( ) The gamma fuctio has the followig properties: If r is ay iteger, the Γ(r) ( ) = (r-)! For ay r, Γ(r+) = r Γ(r) Γ(/) = Statistics-Berli Che 5
52 The Gamma Distributio (/) The pf of the gamma istributio with parameters r > 0 a λ > 0 is r x x e, x 0 f( x) () r. 0, x 0 The mea a variace of Gamma istributio are give by r/ a r/, respectively If,, r are iepeet raom variables, each istribute as xp(λ), the the sum + + r is istribute as a gamma raom variable with parameters r a λ, eote as Γ(r, λ ) Statistics-Berli Che 5
53 The Weibull Distributio (/) The Weibull istributio is a cotiuous raom variable that is use i a variety of situatios A commo applicatio of the Weibull istributio is to moel the lifetimes of compoets The Weibull probability esity fuctio has two parameters, both positive costats, that etermie the locatio a shape. We eote these parameters a If =, the Weibull istributio is the same as the expoetial istributio with parameter λ = Statistics-Berli Che 53
54 The Weibull Distributio (/) The pf of the Weibull istributio is ( x) x e, x 0 f ( x ). 0, x 0 The mea of the Weibull is. The variace of the Weibull is. Statistics-Berli Che 54
55 Probability (Quatile-Quatile) Plots for Fiig a Distributio Scietists a egieers ofte work with ata that ca be thought of as a raom sample from some populatio I may cases, it is importat to etermie the probability istributio ib ti that t approximately escribes the populatio More ofte tha ot, the oly way to etermie a appropriate istributio is to examie the sample to fi a sample istributio that fits Statistics-Berli Che 55
56 Fiig a Distributio (/4) Probability plots are a goo way to etermie a appropriate istributio Here is the iea: Suppose we have a raom sample,, We first arrage the ata i asceig orer The assig icreasig, evely space values betwee 0 a to each i There are several acceptable ways to this; the simplest is to assig the value (i 0.5)/ to i orer statistics The istributio that we are comparig the s to shoul have a mea a variace that match the sample mea a variace We wat to plot ( i, F( i )), if this plot resembles the cf of the istributio that we are itereste i, the we coclue that that is the istributio the ata came from Statistics-Berli Che 56
57 Fiig a Distributio (/4) xample: Give a sample i s arrage i icreasig orer 3.0, 3.35, 4.79, 5.96, 7.89 sample mea 5.00 sample staar eviatio s.00 Q 5 Q 4 Q 3 The curve is the cf of N(5, ). If the sample poits i s came from the istributio, they are likely to lie close to the curve. Q Q Statistics-Berli Che 57
58 Fiig a Distributio (3/4) Whe you use a software package, the it takes the (i 0.5)/ assige to each i a calculates lates the quatile (Qi) correspoig to that umber from the istributio of iterest. The it plots each (i, Qi ), or (mpirical Quatile, Quatile).g., for the previous example (ormal probability plot) Qi Percetile If this plot is a reasoably straight lie the you may coclue that the sample came from the istributio that we use to fi quatiles Statistics-Berli Che 58
59 Fiig a Distributio (4/4) A goo rule of thumb is to require at least 30 poits before relyig o a probability plot.g., a plot of the mothly prouctios of 55 gas wells mothly prouctios atural logs of mothly prouctios The mothly prouctios follow a logormal istributio! Statistics-Berli Che 59
60 The Cetral Limit Theorem (/3) The Cetral Limit Theorem Let,, be a raom sample from a populatio with mea a variace ( is large eough) Let be the sample mea Let S = + + be the sum of the sample observatios. The if is sufficietly large, ~ N, sample mea is approximately ormal! A ~ N (, ) approximately S Statistics-Berli Che 60
61 xample The Cetral Limit Theorem (/3) cotiuous Soli lies: real istributios of sample mea Dashe lies: ormal istributios iscrete somewhat skewe e to the right cotiuous highly skewe to the right Rule of Thumb For most populatios, if the sample size is greater tha 30, the Cetral Limit Theorem approximatio is goo Statistics-Berli Che 6
62 The Cetral Limit Theorem (3/3) xample 4.64: Let eotes the flaws i a i. legth of copper wire, a its correspoig pmf, mea a variace are Oe hure wires are sample from this populatio. What is the probability that the average umber of flow per wire i this sample is less tha 0.5? Followig the cetral limit theorem, we kow that the sample mea ~ N The z - score of 0.5 is 0.66, z. P 0.5 PZ Statistics-Berli Che 6
63 Law of Large Numbers Let,, be a sequece of iepeet raom variables with i a var i. Let. The, for ay, i 0 i P var i var 0, as i 0 var (sice are iepeet) which states that, i i i The esire result follows immeiately from Chebyshev's iequality, P for 0 Statistics-Berli Che 63
64 Normal Approximatio to the Biomial If ~ Bi(,p) a if p > 0, a (-p) ( >0, the ~ N(p, p(-p)) approximately p( p) A p ˆ ~ N p, approximately Bi(00, 0.) approximate by N(0, 6) Recall that ~ where Y Y, Y Bi,p, the ca be represete as Y... Y,,..., Y is a sample from Beroullip Followig the cetral limit theorem, if is large eough the pˆ a Y Y... Y ca be approximate by N p p be approximate by N p, p, p p Statistics-Berli Che 64
65 Normal Approximatio to the Poisso Normal Approximatio to the Poisso: If ~ Poisso(λ), where λ > 0, the ~ N(λ, λ) The Poisso ca be first approximate by Biomial a the by Normal Note that variace of p biomial : p p if p Statistics-Berli Che 65
66 Cotiuity Correctio The biomial istributio is iscrete, while the ormal istributio ib ti is cotiuous The cotiuity correctio is a ajustmet, mae whe approximatig a iscrete istributio with a cotiuous oe, that ca improve the accuracy of the approximatio If you wat to iclue the epoits i your probability calculatio, the exte each epoit by 0.5. The procee with the calculatio e.g., P If you wat exclue the epoits i your probability calculatio, the iclue 0.5 less from each epoit i the calculatio e.g., P45 55 Statistics-Berli Che 66
67 Summary We cosiere various iscrete istributios: Beroulli, Biomial, Poisso, Hypergeometric, Geometric, Negative Biomial, a Multiomial The we looke at some cotiuous istributios: Normal, xpoetial, Gamma, a Weibull We leare about the Cetral Limit Theorem We iscusse Normal approximatios to the Biomial a Poisso istributios tib ti Statistics-Berli Che 67
Chapter 2 Transformations and Expectations
Chapter Trasformatios a Epectatios Chapter Distributios of Fuctios of a Raom Variable Problem: Let be a raom variable with cf F ( ) If we efie ay fuctio of, say g( ) g( ) is also a raom variable whose
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 information(average number of points per unit length). Note that Equation (9B1) does not depend on the
EE603 Class Notes 9/25/203 Joh Stesby Appeix 9-B: Raom Poisso Poits As iscusse i Chapter, let (t,t 2 ) eote the umber of Poisso raom poits i the iterval (t, t 2 ]. The quatity (t, t 2 ) is a o-egative-iteger-value
More informationBinomial Distribution
0.0 0.5 1.0 1.5 2.0 2.5 3.0 0 1 2 3 4 5 6 7 0.0 0.5 1.0 1.5 2.0 2.5 3.0 Overview Example: coi tossed three times Defiitio Formula Recall that a r.v. is discrete if there are either a fiite umber of possible
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 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 informationSTAT 515 fa 2016 Lec Sampling distribution of the mean, part 2 (central limit theorem)
STAT 515 fa 2016 Lec 15-16 Samplig distributio of the mea, part 2 cetral limit theorem Karl B. Gregory Moday, Sep 26th Cotets 1 The cetral limit theorem 1 1.1 The most importat theorem i statistics.............
More informationQuick Review of Probability
Quick Review of Probability Berli Che Departmet of Computer Sciece & Iformatio Egieerig Natioal Taiwa Normal Uiversity Refereces: 1. W. Navidi. Statistics for Egieerig ad Scietists. Chapter & Teachig Material.
More informationConfidence Intervals
Cofidece Itervals Berli Che Deartmet of Comuter Sciece & Iformatio Egieerig Natioal Taiwa Normal Uiversity Referece: 1. W. Navidi. Statistics for Egieerig ad Scietists. Chater 5 & Teachig Material Itroductio
More informationKLMED8004 Medical statistics. Part I, autumn Estimation. We have previously learned: Population and sample. New questions
We have previously leared: KLMED8004 Medical statistics Part I, autum 00 How kow probability distributios (e.g. biomial distributio, ormal distributio) with kow populatio parameters (mea, variace) ca give
More informationClass 27. Daniel B. Rowe, Ph.D. Department of Mathematics, Statistics, and Computer Science. Marquette University MATH 1700
Marquette Uiversity MATH 700 Class 7 Daiel B. Rowe, Ph.D. Departmet of Mathematics, Statistics, a Computer Sciece Copyright 07 by D.B. Rowe Marquette Uiversity MATH 700 Agea: Recap Chapter 0.-0.3 Lecture
More informationParameter, Statistic and Random Samples
Parameter, Statistic ad Radom Samples A parameter is a umber that describes the populatio. It is a fixed umber, but i practice we do ot kow its value. A statistic is a fuctio of the sample data, i.e.,
More informationThe Chi Squared Distribution Page 1
The Chi Square Distributio Page Cosier the istributio of the square of a score take from N(, The probability that z woul have a value less tha is give by z / g ( ( e z if > F π, if < z where ( e g e z
More informationQuick Review of Probability
Quick Review of Probability Berli Che Departmet of Computer Sciece & Iformatio Egieerig Natioal Taiwa Normal Uiversity Refereces: 1. W. Navidi. Statistics for Egieerig ad Scietists. Chapter 2 & Teachig
More informationIE 230 Seat # Name < KEY > Please read these directions. Closed book and notes. 60 minutes.
IE 230 Seat # Name < KEY > Please read these directios. Closed book ad otes. 60 miutes. Covers through the ormal distributio, Sectio 4.7 of Motgomery ad Ruger, fourth editio. Cover page ad four pages of
More informationStatistical Inference (Chapter 10) Statistical inference = learn about a population based on the information provided by a sample.
Statistical Iferece (Chapter 10) Statistical iferece = lear about a populatio based o the iformatio provided by a sample. Populatio: The set of all values of a radom variable X of iterest. Characterized
More informationDiscrete Mathematics for CS Spring 2008 David Wagner Note 22
CS 70 Discrete Mathematics for CS Sprig 2008 David Wager Note 22 I.I.D. Radom Variables Estimatig the bias of a coi Questio: We wat to estimate the proportio p of Democrats i the US populatio, by takig
More informationStat 421-SP2012 Interval Estimation Section
Stat 41-SP01 Iterval Estimatio Sectio 11.1-11. We ow uderstad (Chapter 10) how to fid poit estimators of a ukow parameter. o However, a poit estimate does ot provide ay iformatio about the ucertaity (possible
More information4. Partial Sums and the Central Limit Theorem
1 of 10 7/16/2009 6:05 AM Virtual Laboratories > 6. Radom Samples > 1 2 3 4 5 6 7 4. Partial Sums ad the Cetral Limit Theorem The cetral limit theorem ad the law of large umbers are the two fudametal theorems
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 informationFACULTY OF MATHEMATICAL STUDIES MATHEMATICS FOR PART I ENGINEERING. Lectures
FACULTY OF MATHEMATICAL STUDIES MATHEMATICS FOR PART I ENGINEERING Lectures MODULE 5 STATISTICS II. Mea ad stadard error of sample data. Biomial distributio. Normal distributio 4. Samplig 5. Cofidece itervals
More informationLecture 2: Poisson Sta*s*cs Probability Density Func*ons Expecta*on and Variance Es*mators
Lecture 2: Poisso Sta*s*cs Probability Desity Fuc*os Expecta*o ad Variace Es*mators Biomial Distribu*o: P (k successes i attempts) =! k!( k)! p k s( p s ) k prob of each success Poisso Distributio Note
More informationApproximations and more PMFs and PDFs
Approximatios ad more PMFs ad PDFs Saad Meimeh 1 Approximatio of biomial with Poisso Cosider the biomial distributio ( b(k,,p = p k (1 p k, k λ: k Assume that is large, ad p is small, but p λ at the limit.
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 informationMATH/STAT 352: Lecture 15
MATH/STAT 352: Lecture 15 Sectios 5.2 ad 5.3. Large sample CI for a proportio ad small sample CI for a mea. 1 5.2: Cofidece Iterval for a Proportio Estimatig proportio of successes i a biomial experimet
More information7-1. Chapter 4. Part I. Sampling Distributions and Confidence Intervals
7-1 Chapter 4 Part I. Samplig Distributios ad Cofidece Itervals 1 7- Sectio 1. Samplig Distributio 7-3 Usig Statistics Statistical Iferece: Predict ad forecast values of populatio parameters... Test hypotheses
More informationLecture 2: Monte Carlo Simulation
STAT/Q SCI 43: Itroductio to Resamplig ethods Sprig 27 Istructor: Ye-Chi Che Lecture 2: ote Carlo Simulatio 2 ote Carlo Itegratio Assume we wat to evaluate the followig itegratio: e x3 dx What ca we do?
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 informationStatistics 511 Additional Materials
Cofidece Itervals o mu Statistics 511 Additioal Materials This topic officially moves us from probability to statistics. We begi to discuss makig ifereces about the populatio. Oe way to differetiate probability
More informationEstimation for Complete Data
Estimatio for Complete Data complete data: there is o loss of iformatio durig study. complete idividual complete data= grouped data A complete idividual data is the oe i which the complete iformatio of
More information6. Sufficient, Complete, and Ancillary Statistics
Sufficiet, Complete ad Acillary Statistics http://www.math.uah.edu/stat/poit/sufficiet.xhtml 1 of 7 7/16/2009 6:13 AM Virtual Laboratories > 7. Poit Estimatio > 1 2 3 4 5 6 6. Sufficiet, Complete, ad Acillary
More informationParameter, Statistic and Random Samples
Parameter, Statistic ad Radom Samples A parameter is a umber that describes the populatio. It is a fixed umber, but i practice we do ot kow its value. A statistic is a fuctio of the sample data, i.e.,
More informationRandom Variables, Sampling and Estimation
Chapter 1 Radom Variables, Samplig ad Estimatio 1.1 Itroductio This chapter will cover the most importat basic statistical theory you eed i order to uderstad the ecoometric material that will be comig
More informationDistribution of Random Samples & Limit theorems
STAT/MATH 395 A - PROBABILITY II UW Witer Quarter 2017 Néhémy Lim Distributio of Radom Samples & Limit theorems 1 Distributio of i.i.d. Samples Motivatig example. Assume that the goal of a study is to
More informationStatisticians use the word population to refer the total number of (potential) observations under consideration
6 Samplig Distributios Statisticias use the word populatio to refer the total umber of (potetial) observatios uder cosideratio The populatio is just the set of all possible outcomes i our sample space
More information6.3.3 Parameter Estimation
130 CHAPTER 6. ARMA MODELS 6.3.3 Parameter Estimatio I this sectio we will iscuss methos of parameter estimatio for ARMAp,q assumig that the orers p a q are kow. Metho of Momets I this metho we equate
More information5. Likelihood Ratio Tests
1 of 5 7/29/2009 3:16 PM Virtual Laboratories > 9. Hy pothesis Testig > 1 2 3 4 5 6 7 5. Likelihood Ratio Tests Prelimiaries As usual, our startig poit is a radom experimet with a uderlyig sample space,
More informationChapter 2 Descriptive Statistics
Chapter 2 Descriptive Statistics Statistics Most commoly, statistics refers to umerical data. Statistics may also refer to the process of collectig, orgaizig, presetig, aalyzig ad iterpretig umerical data
More informationSimulation. Two Rule For Inverting A Distribution Function
Simulatio Two Rule For Ivertig A Distributio Fuctio Rule 1. If F(x) = u is costat o a iterval [x 1, x 2 ), the the uiform value u is mapped oto x 2 through the iversio process. Rule 2. If there is a jump
More informationSampling Distributions, Z-Tests, Power
Samplig Distributios, Z-Tests, Power We draw ifereces about populatio parameters from sample statistics Sample proportio approximates populatio proportio Sample mea approximates populatio mea Sample variace
More informationLecture #3. Math tools covered today
Toay s Program:. Review of previous lecture. QM free particle a particle i a bo. 3. Priciple of spectral ecompositio. 4. Fourth Postulate Math tools covere toay Lecture #3. Lear how to solve separable
More informationNOTES ON DISTRIBUTIONS
NOTES ON DISTRIBUTIONS MICHAEL N KATEHAKIS Radom Variables Radom variables represet outcomes from radom pheomea They are specified by two objects The rage R of possible values ad the frequecy fx with which
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 informationStat 225 Lecture Notes Week 7, Chapter 8 and 11
Normal Distributio Stat 5 Lecture Notes Week 7, Chapter 8 ad Please also prit out the ormal radom variable table from the Stat 5 homepage. The ormal distributio is by far the most importat distributio
More informationTopic 10: Introduction to Estimation
Topic 0: Itroductio to Estimatio Jue, 0 Itroductio I the simplest possible terms, the goal of estimatio theory is to aswer the questio: What is that umber? What is the legth, the reactio rate, the fractio
More informationBig Picture. 5. Data, Estimates, and Models: quantifying the accuracy of estimates.
5. Data, Estimates, ad Models: quatifyig the accuracy of estimates. 5. Estimatig a Normal Mea 5.2 The Distributio of the Normal Sample Mea 5.3 Normal data, cofidece iterval for, kow 5.4 Normal data, cofidece
More informationB Supplemental Notes 2 Hypergeometric, Binomial, Poisson and Multinomial Random Variables and Borel Sets
B671-672 Supplemetal otes 2 Hypergeometric, Biomial, Poisso ad Multiomial Radom Variables ad Borel Sets 1 Biomial Approximatio to the Hypergeometric Recall that the Hypergeometric istributio is fx = x
More informationEcon 325/327 Notes on Sample Mean, Sample Proportion, Central Limit Theorem, Chi-square Distribution, Student s t distribution 1.
Eco 325/327 Notes o Sample Mea, Sample Proportio, Cetral Limit Theorem, Chi-square Distributio, Studet s t distributio 1 Sample Mea By Hiro Kasahara We cosider a radom sample from a populatio. Defiitio
More information7.1 Convergence of sequences of random variables
Chapter 7 Limit theorems Throughout this sectio we will assume a probability space (Ω, F, P), i which is defied a ifiite sequece of radom variables (X ) ad a radom variable X. The fact that for every ifiite
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 informationLecture 3. Properties of Summary Statistics: Sampling Distribution
Lecture 3 Properties of Summary Statistics: Samplig Distributio Mai Theme How ca we use math to justify that our umerical summaries from the sample are good summaries of the populatio? Lecture Summary
More informationModeling and Performance Analysis with Discrete-Event Simulation
Simulatio Modelig ad Performace Aalysis with Discrete-Evet Simulatio Chapter 5 Statistical Models i Simulatio Cotets Basic Probability Theory Cocepts Useful Statistical Models Discrete Distributios Cotiuous
More informationA COMPUTATIONAL STUDY UPON THE BURR 2-DIMENSIONAL DISTRIBUTION
TOME VI (year 8), FASCICULE 1, (ISSN 1584 665) A COMPUTATIONAL STUDY UPON THE BURR -DIMENSIONAL DISTRIBUTION MAKSAY Ştefa, BISTRIAN Diaa Alia Uiversity Politehica Timisoara, Faculty of Egieerig Hueoara
More informationJoint Probability Distributions and Random Samples. Jointly Distributed Random Variables. Chapter { }
UCLA STAT A Applied Probability & Statistics for Egieers Istructor: Ivo Diov, Asst. Prof. I Statistics ad Neurology Teachig Assistat: Neda Farziia, UCLA Statistics Uiversity of Califoria, Los Ageles, Sprig
More informationUnderstanding Samples
1 Will Moroe CS 109 Samplig ad Bootstrappig Lecture Notes #17 August 2, 2017 Based o a hadout by Chris Piech I this chapter we are goig to talk about statistics calculated o samples from a populatio. We
More informationSTAC51: Categorical data Analysis
STAC51: Categorical data Aalysis Mahida Samarakoo Jauary 28, 2016 Mahida Samarakoo STAC51: Categorical data Aalysis 1 / 35 Table of cotets Iferece for Proportios 1 Iferece for Proportios Mahida Samarakoo
More information1 of 7 7/16/2009 6:06 AM Virtual Laboratories > 6. Radom Samples > 1 2 3 4 5 6 7 6. Order Statistics Defiitios Suppose agai that we have a basic radom experimet, ad that X is a real-valued radom variable
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 informationInhomogeneous Poisson process
Chapter 22 Ihomogeeous Poisso process We coclue our stuy of Poisso processes with the case of o-statioary rates. Let us cosier a arrival rate, λ(t), that with time, but oe that is still Markovia. That
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 informationIntroduction to Probability and Statistics Twelfth Edition
Itroductio to Probability ad Statistics Twelfth Editio Robert J. Beaver Barbara M. Beaver William Medehall Presetatio desiged ad writte by: Barbara M. Beaver Itroductio to Probability ad Statistics Twelfth
More informationAMS570 Lecture Notes #2
AMS570 Lecture Notes # Review of Probability (cotiued) Probability distributios. () Biomial distributio Biomial Experimet: ) It cosists of trials ) Each trial results i of possible outcomes, S or F 3)
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 informationDiscrete Mathematics for CS Spring 2005 Clancy/Wagner Notes 21. Some Important Distributions
CS 70 Discrete Mathematics for CS Sprig 2005 Clacy/Wager Notes 21 Some Importat Distributios Questio: A biased coi with Heads probability p is tossed repeatedly util the first Head appears. What is the
More informationLecture 12: November 13, 2018
Mathematical Toolkit Autum 2018 Lecturer: Madhur Tulsiai Lecture 12: November 13, 2018 1 Radomized polyomial idetity testig We will use our kowledge of coditioal probability to prove the followig lemma,
More informationWHAT IS THE PROBABILITY FUNCTION FOR LARGE TSUNAMI WAVES? ABSTRACT
WHAT IS THE PROBABILITY FUNCTION FOR LARGE TSUNAMI WAVES? Harold G. Loomis Hoolulu, HI ABSTRACT Most coastal locatios have few if ay records of tsuami wave heights obtaied over various time periods. Still
More informationSTA Learning Objectives. Population Proportions. Module 10 Comparing Two Proportions. Upon completing this module, you should be able to:
STA 2023 Module 10 Comparig Two Proportios Learig Objectives Upo completig this module, you should be able to: 1. Perform large-sample ifereces (hypothesis test ad cofidece itervals) to compare two populatio
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 informationLecture 1 Probability and Statistics
Wikipedia: Lecture 1 Probability ad Statistics Bejami Disraeli, British statesma ad literary figure (1804 1881): There are three kids of lies: lies, damed lies, ad statistics. popularized i US by Mark
More information(7 One- and Two-Sample Estimation Problem )
34 Stat Lecture Notes (7 Oe- ad Two-Sample Estimatio Problem ) ( Book*: Chapter 8,pg65) Probability& Statistics for Egieers & Scietists By Walpole, Myers, Myers, Ye Estimatio 1 ) ( ˆ S P i i Poit estimate:
More informationAdvanced Stochastic Processes.
Advaced Stochastic Processes. David Gamarik LECTURE 2 Radom variables ad measurable fuctios. Strog Law of Large Numbers (SLLN). Scary stuff cotiued... Outlie of Lecture Radom variables ad measurable fuctios.
More informationLecture 6 Simple alternatives and the Neyman-Pearson lemma
STATS 00: Itroductio to Statistical Iferece Autum 06 Lecture 6 Simple alteratives ad the Neyma-Pearso lemma Last lecture, we discussed a umber of ways to costruct test statistics for testig a simple ull
More information(6) Fundamental Sampling Distribution and Data Discription
34 Stat Lecture Notes (6) Fudametal Samplig Distributio ad Data Discriptio ( Book*: Chapter 8,pg5) Probability& Statistics for Egieers & Scietists By Walpole, Myers, Myers, Ye 8.1 Radom Samplig: Populatio:
More informationTopic 9: Sampling Distributions of Estimators
Topic 9: Samplig Distributios of Estimators Course 003, 2016 Page 0 Samplig distributios of estimators Sice our estimators are statistics (particular fuctios of radom variables), their distributio ca be
More informationf(x i ; ) L(x; p) = i=1 To estimate the value of that maximizes L or equivalently ln L we will set =0, for i =1, 2,...,m p x i (1 p) 1 x i i=1
Parameter Estimatio Samples from a probability distributio F () are: [,,..., ] T.Theprobabilitydistributio has a parameter vector [,,..., m ] T. Estimator: Statistic used to estimate ukow. Estimate: Observed
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 information1 Review and Overview
CS229T/STATS231: Statistical Learig Theory Lecturer: Tegyu Ma Lecture #12 Scribe: Garrett Thomas, Pega Liu October 31, 2018 1 Review a Overview Recall the GAN setup: we have iepeet samples x 1,..., x raw
More information11/19/ Chapter 10 Overview. Chapter 10: Two-Sample Inference. + The Big Picture : Inference for Mean Difference Dependent Samples
/9/0 + + Chapter 0 Overview Dicoverig Statitic Eitio Daiel T. Laroe Chapter 0: Two-Sample Iferece 0. Iferece for Mea Differece Depeet Sample 0. Iferece for Two Iepeet Mea 0.3 Iferece for Two Iepeet Proportio
More informationIE 230 Probability & Statistics in Engineering I. Closed book and notes. No calculators. 120 minutes.
Closed book ad otes. No calculators. 120 miutes. Cover page, five pages of exam, ad tables for discrete ad cotiuous distributios. Score X i =1 X i / S X 2 i =1 (X i X ) 2 / ( 1) = [i =1 X i 2 X 2 ] / (
More informationTopic 9: Sampling Distributions of Estimators
Topic 9: Samplig Distributios of Estimators Course 003, 2018 Page 0 Samplig distributios of estimators Sice our estimators are statistics (particular fuctios of radom variables), their distributio ca be
More informationLecture 5. Random variable and distribution of probability
Itroductio to theory of probability ad statistics Lecture 5. Radom variable ad distributio of probability prof. dr hab.iż. Katarzya Zarzewsa Katedra Eletroii, AGH e-mail: za@agh.edu.pl http://home.agh.edu.pl/~za
More informationClosed book and notes. No calculators. 60 minutes, but essentially unlimited time.
IE 230 Seat # Closed book ad otes. No calculators. 60 miutes, but essetially ulimited time. Cover page, four pages of exam, ad Pages 8 ad 12 of the Cocise Notes. This test covers through Sectio 4.7 of
More informationDiscrete Mathematics and Probability Theory Spring 2012 Alistair Sinclair Note 15
CS 70 Discrete Mathematics ad Probability Theory Sprig 2012 Alistair Siclair Note 15 Some Importat Distributios The first importat distributio we leared about i the last Lecture Note is the biomial distributio
More information7.1 Convergence of sequences of random variables
Chapter 7 Limit Theorems Throughout this sectio we will assume a probability space (, F, P), i which is defied a ifiite sequece of radom variables (X ) ad a radom variable X. The fact that for every ifiite
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 informationIf, for instance, we were required to test whether the population mean μ could be equal to a certain value μ
STATISTICAL INFERENCE INTRODUCTION Statistical iferece is that brach of Statistics i which oe typically makes a statemet about a populatio based upo the results of a sample. I oesample testig, we essetially
More informationHOMEWORK I: PREREQUISITES FROM MATH 727
HOMEWORK I: PREREQUISITES FROM MATH 727 Questio. Let X, X 2,... be idepedet expoetial radom variables with mea µ. (a) Show that for Z +, we have EX µ!. (b) Show that almost surely, X + + X (c) Fid the
More information6.3 Testing Series With Positive Terms
6.3. TESTING SERIES WITH POSITIVE TERMS 307 6.3 Testig Series With Positive Terms 6.3. Review of what is kow up to ow I theory, testig a series a i for covergece amouts to fidig the i= sequece of partial
More informationTopic 9: Sampling Distributions of Estimators
Topic 9: Samplig Distributios of Estimators Course 003, 2018 Page 0 Samplig distributios of estimators Sice our estimators are statistics (particular fuctios of radom variables), their distributio ca be
More informationOverview of Estimation
Topic Iferece is the problem of turig data ito kowledge, where kowledge ofte is expressed i terms of etities that are ot preset i the data per se but are preset i models that oe uses to iterpret the data.
More informationChapter 22. Comparing Two Proportions. Copyright 2010, 2007, 2004 Pearson Education, Inc.
Chapter 22 Comparig Two Proportios Copyright 2010, 2007, 2004 Pearso Educatio, Ic. Comparig Two Proportios Read the first two paragraphs of pg 504. Comparisos betwee two percetages are much more commo
More informationStatistics 300: Elementary Statistics
Statistics 300: Elemetary Statistics Sectios 7-, 7-3, 7-4, 7-5 Parameter Estimatio Poit Estimate Best sigle value to use Questio What is the probability this estimate is the correct value? Parameter Estimatio
More informationProbability in Medical Imaging
Chapter P Probability i Meical Imagig Cotets Itrouctio P1 Probability a isotropic emissios P2 Raioactive ecay statistics P4 Biomial coutig process P4 Half-life P5 Poisso process P6 Determiig activity of
More informationDS 100: Principles and Techniques of Data Science Date: April 13, Discussion #10
DS 00: Priciples ad Techiques of Data Sciece Date: April 3, 208 Name: Hypothesis Testig Discussio #0. Defie these terms below as they relate to hypothesis testig. a) Data Geeratio Model: Solutio: A set
More informationCH5. Discrete Probability Distributions
CH5. Discrete Probabilit Distributios Radom Variables A radom variable is a fuctio or rule that assigs a umerical value to each outcome i the sample space of a radom eperimet. Nomeclature: - Capital letters:
More informationRead through these prior to coming to the test and follow them when you take your test.
Math 143 Sprig 2012 Test 2 Iformatio 1 Test 2 will be give i class o Thursday April 5. Material Covered The test is cummulative, but will emphasize the recet material (Chapters 6 8, 10 11, ad Sectios 12.1
More informationLecture 4. Random variable and distribution of probability
Itroductio to theory of probability ad statistics Lecture. Radom variable ad distributio of probability dr hab.iż. Katarzya Zarzewsa, prof.agh Katedra Eletroii, AGH e-mail: za@agh.edu.pl http://home.agh.edu.pl/~za
More information4. Basic probability theory
Cotets Basic cocepts Discrete radom variables Discrete distributios (br distributios) Cotiuous radom variables Cotiuous distributios (time distributios) Other radom variables Lect04.ppt S-38.45 - Itroductio
More informationThe structure of Fourier series
The structure of Fourier series Valery P Dmitriyev Lomoosov Uiversity, Russia Date: February 3, 2011) Fourier series is costructe basig o the iea to moel the elemetary oscillatio 1, +1) by the expoetial
More informationENGI Series Page 6-01
ENGI 3425 6 Series Page 6-01 6. Series Cotets: 6.01 Sequeces; geeral term, limits, covergece 6.02 Series; summatio otatio, covergece, divergece test 6.03 Stadard Series; telescopig series, geometric series,
More information