A Study of Non-Central Skew T Distributions and Their Applications in Data Analysis and Change Point Detection
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Hypothesis Testing and Likelihood Ratio Tests
Hypottthesiiis tttestttiiing and llliiikellliiihood ratttiiio tttesttts Y We will adopt the following model for observed data. The distribution of Y = (Y1, ..., Yn) is parameter considered known except for some paramett er ç, which may be a vector ç = (ç1, ..., çk); ç“Ç, the paramettter space. The parameter space will usually be an open set. If Y is a continuous random variable, its probabiiillliiittty densiiittty functttiiion (pdf) will de denoted f(yy;ç) . If Y is y probability mass function y Y y discrete then f(yy;ç) represents the probabii ll ii tt y mass functt ii on (pmf); f(yy;ç) = Pç(YY=yy). A stttatttiiistttiiicalll hypottthesiiis is a statement about the value of ç. We are interested in testing the null hypothesis H0: ç“Ç0 versus the alternative hypothesis H1: ç“Ç1. Where Ç0 and Ç1 ¶ Ç. hypothesis test Naturally Ç0 § Ç1 = ∅, but we need not have Ç0 ∞ Ç1 = Ç. A hypott hesii s tt estt is a procedure critical region for deciding between H0 and H1 based on the sample data. It is equivalent to a crii tt ii call regii on: a critical region is a set C ¶ Rn y such that if y = (y1, ..., yn) “ C, H0 is rejected. Typically C is expressed in terms of the value of some tttesttt stttatttiiistttiiic, a function of the sample data. For µ example, we might have C = {(y , ..., y ): y – 0 ≥ 3.324}. The number 3.324 here is called a 1 n s/ n µ criiitttiiicalll valllue of the test statistic Y – 0 . S/ n If y“C but ç“Ç 0, we have committed a Type I error. -
Data 8 Final Stats Review
Data 8 Final Stats review I. Hypothesis Testing Purpose: To answer a question about a process or the world by testing two hypotheses, a null and an alternative. Usually the null hypothesis makes a statement that “the world/process works this way”, and the alternative hypothesis says “the world/process does not work that way”. Examples: Null: “The customer was not cheating-his chances of winning and losing were like random tosses of a fair coin-50% chance of winning, 50% of losing. Any variation from what we expect is due to chance variation.” Alternative: “The customer was cheating-his chances of winning were something other than 50%”. Pro tip: You must be very precise about chances in your hypotheses. Hypotheses such as “the customer cheated” or “Their chances of winning were normal” are vague and might be considered incorrect, because you don’t state the exact chances associated with the events. Pro tip: Null hypothesis should also explain differences in the data. For example, if your hypothesis stated that the coin was fair, then why did you get 70 heads out of 100 flips? Since it’s possible to get that many (though not expected), your null hypothesis should also contain a statement along the lines of “Any difference in outcome from what we expect is due to chance variation”. Steps: 1) Precisely state your null and alternative hypotheses. 2) Decide on a test statistic (think of it as a general formula) to help you either reject or fail to reject the null hypothesis. • If your data is categorical, a good test statistic might be the Total Variation Distance (TVD) between your sample and the distribution it was drawn from. -
Use of Statistical Tables
TUTORIAL | SCOPE USE OF STATISTICAL TABLES Lucy Radford, Jenny V Freeman and Stephen J Walters introduce three important statistical distributions: the standard Normal, t and Chi-squared distributions PREVIOUS TUTORIALS HAVE LOOKED at hypothesis testing1 and basic statistical tests.2–4 As part of the process of statistical hypothesis testing, a test statistic is calculated and compared to a hypothesised critical value and this is used to obtain a P- value. This P-value is then used to decide whether the study results are statistically significant or not. It will explain how statistical tables are used to link test statistics to P-values. This tutorial introduces tables for three important statistical distributions (the TABLE 1. Extract from two-tailed standard Normal, t and Chi-squared standard Normal table. Values distributions) and explains how to use tabulated are P-values corresponding them with the help of some simple to particular cut-offs and are for z examples. values calculated to two decimal places. STANDARD NORMAL DISTRIBUTION TABLE 1 The Normal distribution is widely used in statistics and has been discussed in z 0.00 0.01 0.02 0.03 0.050.04 0.05 0.06 0.07 0.08 0.09 detail previously.5 As the mean of a Normally distributed variable can take 0.00 1.0000 0.9920 0.9840 0.9761 0.9681 0.9601 0.9522 0.9442 0.9362 0.9283 any value (−∞ to ∞) and the standard 0.10 0.9203 0.9124 0.9045 0.8966 0.8887 0.8808 0.8729 0.8650 0.8572 0.8493 deviation any positive value (0 to ∞), 0.20 0.8415 0.8337 0.8259 0.8181 0.8103 0.8206 0.7949 0.7872 0.7795 0.7718 there are an infinite number of possible 0.30 0.7642 0.7566 0.7490 0.7414 0.7339 0.7263 0.7188 0.7114 0.7039 0.6965 Normal distributions. -
A Skew Extension of the T-Distribution, with Applications
J. R. Statist. Soc. B (2003) 65, Part 1, pp. 159–174 A skew extension of the t-distribution, with applications M. C. Jones The Open University, Milton Keynes, UK and M. J. Faddy University of Birmingham, UK [Received March 2000. Final revision July 2002] Summary. A tractable skew t-distribution on the real line is proposed.This includes as a special case the symmetric t-distribution, and otherwise provides skew extensions thereof.The distribu- tion is potentially useful both for modelling data and in robustness studies. Properties of the new distribution are presented. Likelihood inference for the parameters of this skew t-distribution is developed. Application is made to two data modelling examples. Keywords: Beta distribution; Likelihood inference; Robustness; Skewness; Student’s t-distribution 1. Introduction Student’s t-distribution occurs frequently in statistics. Its usual derivation and use is as the sam- pling distribution of certain test statistics under normality, but increasingly the t-distribution is being used in both frequentist and Bayesian statistics as a heavy-tailed alternative to the nor- mal distribution when robustness to possible outliers is a concern. See Lange et al. (1989) and Gelman et al. (1995) and references therein. It will often be useful to consider a further alternative to the normal or t-distribution which is both heavy tailed and skew. To this end, we propose a family of distributions which includes the symmetric t-distributions as special cases, and also includes extensions of the t-distribution, still taking values on the whole real line, with non-zero skewness. Let a>0 and b>0be parameters. -
On Moments of Folded and Truncated Multivariate Normal Distributions
On Moments of Folded and Truncated Multivariate Normal Distributions Raymond Kan Rotman School of Management, University of Toronto 105 St. George Street, Toronto, Ontario M5S 3E6, Canada (E-mail: [email protected]) and Cesare Robotti Terry College of Business, University of Georgia 310 Herty Drive, Athens, Georgia 30602, USA (E-mail: [email protected]) April 3, 2017 Abstract Recurrence relations for integrals that involve the density of multivariate normal distributions are developed. These recursions allow fast computation of the moments of folded and truncated multivariate normal distributions. Besides being numerically efficient, the proposed recursions also allow us to obtain explicit expressions of low order moments of folded and truncated multivariate normal distributions. Keywords: Multivariate normal distribution; Folded normal distribution; Truncated normal distribution. 1 Introduction T Suppose X = (X1;:::;Xn) follows a multivariate normal distribution with mean µ and k kn positive definite covariance matrix Σ. We are interested in computing E(jX1j 1 · · · jXnj ) k1 kn and E(X1 ··· Xn j ai < Xi < bi; i = 1; : : : ; n) for nonnegative integer values ki = 0; 1; 2;:::. The first expression is the moment of a folded multivariate normal distribution T jXj = (jX1j;:::; jXnj) . The second expression is the moment of a truncated multivariate normal distribution, with Xi truncated at the lower limit ai and upper limit bi. In the second expression, some of the ai's can be −∞ and some of the bi's can be 1. When all the bi's are 1, the distribution is called the lower truncated multivariate normal, and when all the ai's are −∞, the distribution is called the upper truncated multivariate normal. -
5. the Student T Distribution
Virtual Laboratories > 4. Special Distributions > 1 2 3 4 5 6 7 8 9 10 11 12 13 14 15 5. The Student t Distribution In this section we will study a distribution that has special importance in statistics. In particular, this distribution will arise in the study of a standardized version of the sample mean when the underlying distribution is normal. The Probability Density Function Suppose that Z has the standard normal distribution, V has the chi-squared distribution with n degrees of freedom, and that Z and V are independent. Let Z T= √V/n In the following exercise, you will show that T has probability density function given by −(n +1) /2 Γ((n + 1) / 2) t2 f(t)= 1 + , t∈ℝ ( n ) √n π Γ(n / 2) 1. Show that T has the given probability density function by using the following steps. n a. Show first that the conditional distribution of T given V=v is normal with mean 0 a nd variance v . b. Use (a) to find the joint probability density function of (T,V). c. Integrate the joint probability density function in (b) with respect to v to find the probability density function of T. The distribution of T is known as the Student t distribution with n degree of freedom. The distribution is well defined for any n > 0, but in practice, only positive integer values of n are of interest. This distribution was first studied by William Gosset, who published under the pseudonym Student. In addition to supplying the proof, Exercise 1 provides a good way of thinking of the t distribution: the t distribution arises when the variance of a mean 0 normal distribution is randomized in a certain way. -
8.5 Testing a Claim About a Standard Deviation Or Variance
8.5 Testing a Claim about a Standard Deviation or Variance Testing Claims about a Population Standard Deviation or a Population Variance ² Uses the chi-squared distribution from section 7-4 → Requirements: 1. The sample is a simple random sample 2. The population has a normal distribution (n −1)s 2 → Test Statistic for Testing a Claim about or ²: 2 = 2 where n = sample size s = sample standard deviation σ = population standard deviation s2 = sample variance σ2 = population variance → P-values and Critical Values: Use table A-4 with df = n – 1 for the number of degrees of freedom *Remember that table A-4 is based on cumulative areas from the right → Properties of the Chi-Square Distribution: 1. All values of 2 are nonnegative and the distribution is not symmetric 2. There is a different 2 distribution for each number of degrees of freedom 3. The critical values are found in table A-4 (based on cumulative areas from the right) --locate the row corresponding to the appropriate number of degrees of freedom (df = n – 1) --the significance level is used to determine the correct column --Right-tailed test: Because the area to the right of the critical value is 0.05, locate 0.05 at the top of table A-4 --Left-tailed test: With a left-tailed area of 0.05, the area to the right of the critical value is 0.95 so locate 0.95 at the top of table A-4 --Two-tailed test: Divide the significance level of 0.05 between the left and right tails, so the areas to the right of the two critical values are 0.975 and 0.025. -
On the Meaning and Use of Kurtosis
Psychological Methods Copyright 1997 by the American Psychological Association, Inc. 1997, Vol. 2, No. 3,292-307 1082-989X/97/$3.00 On the Meaning and Use of Kurtosis Lawrence T. DeCarlo Fordham University For symmetric unimodal distributions, positive kurtosis indicates heavy tails and peakedness relative to the normal distribution, whereas negative kurtosis indicates light tails and flatness. Many textbooks, however, describe or illustrate kurtosis incompletely or incorrectly. In this article, kurtosis is illustrated with well-known distributions, and aspects of its interpretation and misinterpretation are discussed. The role of kurtosis in testing univariate and multivariate normality; as a measure of departures from normality; in issues of robustness, outliers, and bimodality; in generalized tests and estimators, as well as limitations of and alternatives to the kurtosis measure [32, are discussed. It is typically noted in introductory statistics standard deviation. The normal distribution has a kur- courses that distributions can be characterized in tosis of 3, and 132 - 3 is often used so that the refer- terms of central tendency, variability, and shape. With ence normal distribution has a kurtosis of zero (132 - respect to shape, virtually every textbook defines and 3 is sometimes denoted as Y2)- A sample counterpart illustrates skewness. On the other hand, another as- to 132 can be obtained by replacing the population pect of shape, which is kurtosis, is either not discussed moments with the sample moments, which gives or, worse yet, is often described or illustrated incor- rectly. Kurtosis is also frequently not reported in re- ~(X i -- S)4/n search articles, in spite of the fact that virtually every b2 (•(X i - ~')2/n)2' statistical package provides a measure of kurtosis. -
A Multivariate Student's T-Distribution
Open Journal of Statistics, 2016, 6, 443-450 Published Online June 2016 in SciRes. http://www.scirp.org/journal/ojs http://dx.doi.org/10.4236/ojs.2016.63040 A Multivariate Student’s t-Distribution Daniel T. Cassidy Department of Engineering Physics, McMaster University, Hamilton, ON, Canada Received 29 March 2016; accepted 14 June 2016; published 17 June 2016 Copyright © 2016 by author and Scientific Research Publishing Inc. This work is licensed under the Creative Commons Attribution International License (CC BY). http://creativecommons.org/licenses/by/4.0/ Abstract A multivariate Student’s t-distribution is derived by analogy to the derivation of a multivariate normal (Gaussian) probability density function. This multivariate Student’s t-distribution can have different shape parameters νi for the marginal probability density functions of the multi- variate distribution. Expressions for the probability density function, for the variances, and for the covariances of the multivariate t-distribution with arbitrary shape parameters for the marginals are given. Keywords Multivariate Student’s t, Variance, Covariance, Arbitrary Shape Parameters 1. Introduction An expression for a multivariate Student’s t-distribution is presented. This expression, which is different in form than the form that is commonly used, allows the shape parameter ν for each marginal probability density function (pdf) of the multivariate pdf to be different. The form that is typically used is [1] −+ν Γ+((ν n) 2) T ( n) 2 +Σ−1 n 2 (1.[xx] [ ]) (1) ΓΣ(νν2)(π ) This “typical” form attempts to generalize the univariate Student’s t-distribution and is valid when the n marginal distributions have the same shape parameter ν . -
The Normal Moment Generating Function
MSc. Econ: MATHEMATICAL STATISTICS, 1996 The Moment Generating Function of the Normal Distribution Recall that the probability density function of a normally distributed random variable x with a mean of E(x)=and a variance of V (x)=2 is 2 1 1 (x)2/2 (1) N(x; , )=p e 2 . (22) Our object is to nd the moment generating function which corresponds to this distribution. To begin, let us consider the case where = 0 and 2 =1. Then we have a standard normal, denoted by N(z;0,1), and the corresponding moment generating function is dened by Z zt zt 1 1 z2 Mz(t)=E(e )= e √ e 2 dz (2) 2 1 t2 = e 2 . To demonstate this result, the exponential terms may be gathered and rear- ranged to give exp zt exp 1 z2 = exp 1 z2 + zt (3) 2 2 1 2 1 2 = exp 2 (z t) exp 2 t . Then Z 1t2 1 1(zt)2 Mz(t)=e2 √ e 2 dz (4) 2 1 t2 = e 2 , where the nal equality follows from the fact that the expression under the integral is the N(z; = t, 2 = 1) probability density function which integrates to unity. Now consider the moment generating function of the Normal N(x; , 2) distribution when and 2 have arbitrary values. This is given by Z xt xt 1 1 (x)2/2 (5) Mx(t)=E(e )= e p e 2 dx (22) Dene x (6) z = , which implies x = z + . 1 MSc. Econ: MATHEMATICAL STATISTICS: BRIEF NOTES, 1996 Then, using the change-of-variable technique, we get Z 1 1 2 dx t zt p 2 z Mx(t)=e e e dz 2 dz Z (2 ) (7) t zt 1 1 z2 = e e √ e 2 dz 2 t 1 2t2 = e e 2 , Here, to establish the rst equality, we have used dx/dz = . -
A Family of Skew-Normal Distributions for Modeling Proportions and Rates with Zeros/Ones Excess
S S symmetry Article A Family of Skew-Normal Distributions for Modeling Proportions and Rates with Zeros/Ones Excess Guillermo Martínez-Flórez 1, Víctor Leiva 2,* , Emilio Gómez-Déniz 3 and Carolina Marchant 4 1 Departamento de Matemáticas y Estadística, Facultad de Ciencias Básicas, Universidad de Córdoba, Montería 14014, Colombia; [email protected] 2 Escuela de Ingeniería Industrial, Pontificia Universidad Católica de Valparaíso, 2362807 Valparaíso, Chile 3 Facultad de Economía, Empresa y Turismo, Universidad de Las Palmas de Gran Canaria and TIDES Institute, 35001 Canarias, Spain; [email protected] 4 Facultad de Ciencias Básicas, Universidad Católica del Maule, 3466706 Talca, Chile; [email protected] * Correspondence: [email protected] or [email protected] Received: 30 June 2020; Accepted: 19 August 2020; Published: 1 September 2020 Abstract: In this paper, we consider skew-normal distributions for constructing new a distribution which allows us to model proportions and rates with zero/one inflation as an alternative to the inflated beta distributions. The new distribution is a mixture between a Bernoulli distribution for explaining the zero/one excess and a censored skew-normal distribution for the continuous variable. The maximum likelihood method is used for parameter estimation. Observed and expected Fisher information matrices are derived to conduct likelihood-based inference in this new type skew-normal distribution. Given the flexibility of the new distributions, we are able to show, in real data scenarios, the good performance of our proposal. Keywords: beta distribution; centered skew-normal distribution; maximum-likelihood methods; Monte Carlo simulations; proportions; R software; rates; zero/one inflated data 1. -
A Study of Ocean Wave Statistical Properties Using SNOW
A study of ocean wave statistical properties using nonlinear, directional, phase- resolved ocean wavefield simulations Legena Henry PhD Candidate Course 2 – OE [email protected] abstract We study the statistics of wavefields obtained from phase-resolved simulations that are non-linear (up to the third order in surface potential). We model wave-wave interactions based on the fully non- linear Zakharov equations. We vary the simulated wavefield's input spectral properties: peak shape parameter, Phillips parameter and Directional Spreading Function. We then investigate the relationships between these input spectral properties and output physical properties via statistical analysis. We investigate: 1. Surface elevation distribution in response to input spectral properties, 2. Wave definition methods in an irregular wavefield with a two- dimensional wave number, 3. Wave height/wavelength distributions in response to input spectral properties, including the occurrence and spacing of large wave events (based on definitions in 2). 1. Surface elevation distribution in response to input spectral properties: – Peak Shape Parameter – Phillips' Parameter – Directional Spreading Function 1. Surface elevation distribution in response to input spectral properties: Peak shape parameter Peak shape parameter produces higher impact on even moments of surface elevation, (i.e. surface elevation kurtosis and surface elevation variance) than on the observed odd moments (skewness) of surface elevation. The highest elevations in a wavefield with mean peak shape parameter, 3.3 are more stable than those in wavefields with mean peak shape parameter, 1.0, and 5.0 We find surface elevation kurtosis in non-linear wavefields is much smaller than surface elevation slope kurtosis. We also see that higher values of peak shape parameter produce higher kurtosis of surface slope in the mean direction of propagation.