Conjugacy and the Exponential Family
|
|
- Marsha Golden
- 5 years ago
- Views:
Transcription
1 CS281B/Stat241B: Advanced Topcs n Learnng & Decson Makng Conjugacy and the Exponental Famly Lecturer: Mchael I. Jordan Scrbes: Bran Mlch 1 Conjugacy In the prevous lecture, we saw conjugate prors for the multvarate Gaussan dstrbuton. In ths lecture, we dscuss conjugacy more generally. A famly of probablty dstrbutons P s conjugate for a probablty model p f the posteror les n P whenever the pror les n P. Note that the famly of all probablty dstrbutons s conjugate for any model p. What f we have a probablty model p(y θ) for some practcal problem, but the standard conjugate famly for p does not seem to contan a realstc pror dstrbuton? One thng we can do s use a mxture model as our pror: k p(θ) = α j p j (θ) =1 where 0 α 1, α = 1, and each p j (θ) s n a famly P j that s conjugate for p(y θ). If we multply ths p(θ) by p(y θ), then each p j (θ) s multpled by p(y θ), yeldng another dstrbuton n P j. So the posteror p(θ y) s a mxture of the same form. The same result holds for an nfnte mxture ndexed by a contnuous parameter τ: p(θ) = g(τ)p(θ; τ) dτ where g(τ) s an arbtrary densty functon. We can also take a lmt of ncreasngly flat conjugate prors, yeldng an mproper pror wth densty 1 everywhere. Ths s the ultmate unnformatve pror, but t s mproper n that t does not ntegrate to 1. If we multply t by a p(y θ) dstrbuton, such as a Gaussan, the resultng posteror may ntegrate to 1 and thus be a true densty. However, ths s not guaranteed for all choces of p(y θ). If we use a mxture model, how can we set the α s? To be fully Bayesan, we should set them based on some background knowledge. However, a common technque s emprcal Bayes: estmate the α s by maxmum lkelhood on the tranng data. 2 The Exponental Famly For a fully general treatment of conjugate prors, we turn to a very large famly of dstrbutons called the exponental famly, whch actually contans every parametrc famly of dstrbutons. The general form of an exponental famly dstrbuton s: p(x θ) = h(x) exp ( φ(θ) T (x) A(θ) ) (1) Here φ(θ) s the canoncal parameter, often denoted η. T (x) s the suffcent statstc, and A(θ) s the cumulant generatng functon or log partton functon. The x here can range over any set, as long as T (x) 1
2 2 Conjugacy and the Exponental Famly maps each x to a vector of fxed, fnte dmenson. p(x θ) s a densty wth respect to some underlyng measure µ. The h(x) functon can just be thought of as an adjustment to ths underlyng measure, and s not usually mportant. Snce the expresson n Eq. 1 s a densty, t must ntegrate to 1: h(x)e η T (x) A(θ) dx = 1 where η = φ(θ). Therefore: A(θ) = ln h(x)e η T (x) dx (2) So A(θ) s fully determned by η and T (x). It can be shown that the set of vald η vectors {η : h(x)e η T (x) dx < } s convex. So convex combnatons of vald parameter vectors are also vald parameter vectors. Also, optmzng over the set of vald η s s not too dffcult. So far we have wrtten the cumulant generatng functon as A(θ). We can also wrte t as A(η), usng a dfferent functon A. We wll lmt ourselves to cases where φ(θ) s one-to-one. The second convexty property of the exponental famly s that A(η) s always a convex functon of η. Ths follows from a general convex analyss result about log-sum-exp equaltes such as Eq. 2. A(η) s called the cumulant generatng functon because ts dervatves wth respect to η are the cumulants (central moments,.e., mean, varance, kurtoss, etc.) of the suffcent statstc T (X). For the frst cumulant, we take the frst dervatve: h(x)e η T (x) T (x) dx A(η) = h(x)e η T (x) dx By Eq. 2, the denomnator s e A(η), so: A(η) = h(x)e η T (x) A(η) T (x) dx = ET (x) Smlarly, the Hessan matrx 2 A(η) s the covarance matrx Var(T (x)). Thus, to fnd the cumulants of an exponental famly dstrbuton wth a gven A(η), we don t have to do messy ntegrals; we just have to take dervatves. For more nformaton on the exponental famly, see the recent techncal report by Wanwrght and Jordan, Graphcal models, exponental famles, and varatonal nference (avalable from Prof. Jordan s web page). A good book on the subject s by Lawrence Brown, Fundamentals of Statstcal Exponental Famles, publshed n the IMS Lecture Notes seres n The exponental famly s qute powerful: t ncludes all the standard dstrbutons such as the Bernoull, Gaussan, gamma, Posson, Ralegh, etc. However, exponental famly dstrbutons are parametrc: the parameter vector η has a fxed dmenson. 2.1 Conjugacy and the exponental famly Consder the setup n Fg. 1, where we take n samples y from an exponental famly dstrbuton: p(y θ) = h(y ) exp ( φ(θ) T (y ) A(θ) ) (3) Let y be the random vector formed by concatenatng all the samples y. Then: ( ) ( p(y θ) = h(y ) exp φ(θ) ) T (y ) na(θ) (4)
3 Conjugacy and the Exponental Famly 3 µ ν θ Y n Fgure 1: Graphcal model for an exponental famly dstrbuton and ts conjugate pror. Thus, y also has an exponental famly dstrbuton: t has the same canoncal parameter φ(θ); ts suffcent statstc s T (y ); and ts cumulant generatng functon s na(θ). We can construct a conjugate famly of pror dstrbutons as follows, wth two parameters µ and ν: p(θ µ, ν) exp ( φ(θ) µ νa(θ) ) (5) Then the posteror dstrbuton s: ( p(θ y, µ, ν) exp (φ(θ) µ + ) ) T (y ) (n + ν)a(θ) (6) We can also take a herarchcal Bayesan approach, puttng prors on µ and ν as well. It s worth notng that ths s just the mnmal conjugate famly for p(y θ), n the sense that s has a mnmal number of parameters. Of course there are other conjugate famles, such as the famly of mxtures of these dstrbutons, and the famly of all dstrbutons. 2.2 ML estmaton of mean parameters Puttng asde the Bayesan approach for the moment, suppose we want a maxmum lkelhood (ML) estmate of the mean parameter µ = ET (X) for some exponental famly dstrbuton. Ths µ s a functon of η: specfcally µ = η A(η). So t suffces to maxmze the lkelhood wth respect to η. Based on Eq. 4, the log lkelhood s: l(η; y) = η n =1 T (y ) na(η) + c(y) (7) where c(y) s some functon that does not depend on η. Dfferentatng wth respect to η, we get: η l = = n T (y ) n η A(η) =1 n T (y ) net (X) =1 Settng ths to zero, we get: ˆµ ML = 1 n n T (y ) (8) In other words, the maxmum lkelhood estmate for the expectaton of the suffcent statstc s just the emprcal mean of the suffcent statstc. We already knew ths fact for common dstrbutons such as the Gaussan, Posson, etc.; now we have a general proof. =1
4 4 Conjugacy and the Exponental Famly 2.3 Exercses wth the exponental famly Here are some exercses for the reader nvolvng the exponental famly. Consder the Posson dstrbuton: and the bnomal dstrbuton (wth a fxed n): p(x θ) = p(x θ) = θx e θ x! ( ) n θ x (1 θ) n x x Express each of these dstrbutons n exponental famly form. For example, the canoncal parameter η for the bnomal dstrbuton s ln θ 1 θ. Compute A(θ), and then dfferentate t to obtan the mean µ for each dstrbuton. 2.4 Parameterzatons We have seen several ways of parameterzng the exponental famly, that s, ndexng the set of exponental famly dstrbutons. There s the canoncal parameter η, and also the mean parameter µ = ET (X). Recall that A(η) s a convex functon, so µ = η A(η) s nondecreasng n η. If A(η) s strctly convex, then η A(η) s ncreasng n η, and therefore the mappng between η and µ s one-to-one. See Fg. 2 for an llustraton of ths relatonshp. A(η) slope µ Fgure 2: If η s one-dmensonal, then the mean parameter µ correspondng to η s just the slope of a tangent lne to the cumulant generatng functon A evaluated at η. We have also used another parameter, denoted θ to ndex the set of exponental famly dstrbutons. Ths parameter does not have a specal name; t s just some parameter that s convenent for defnng the dstrbuton. η 3 The Exponental Famly and Graphcal Models 3.1 The Isng model The prevous course n ths sequence dealt wth probablstc graphcal models. We can also thnk of graphcal models as defnng exponental famly dstrbutons. As an example, consder the Isng model, llustrated n Fg. 3. Ths model comes from statstcal physcs, where each node represents the spn (up or down) of a partcle. We represent each partcle s spn wth a varable X takng values {0, 1} (we can formulate an equvalent model wth { 1, 1}). The parameters are θ, representng the external feld on partcle, and θ j, representng the attracton between partcles and j. If and j are not adjacent n the graph, then θ j = 0.
5 Conjugacy and the Exponental Famly 5 X 1 X 2 X n Fgure 3: An Isng model wth n = 9 nodes The probablty dstrbuton s: p(x θ) = exp θ j x x j + <j θ x A(θ) = 1 Z(θ) exp θ j x x j + <j θ x where Z(θ) s the partton functon. Ths s an exponental famly dstrbuton where the suffcent statstc T (x) conssts of all the values x and x x j (for < j) concatenated together. So f µ ET (X), then µ = EX and µ j = EX X j. Thus, the µ vector contans the expectatons and correlatons of the partcles spns. It can be shown that A(η) s strctly convex, so there s a one-to-one mappng between η and µ. However, actually computng µ from η s #P-hard. In fact, we can thnk of the whole problem of probablstc nference as computng the mean parameter µ from the canoncal parameter η (or some other parameter θ). Of course, ths problem s #P-hard n general. 3.2 Graphcal models n general In an undrected graphcal model, we specfy a potental ψ C for each clque C of the graph. The jont probablty dstrbuton s then gven by: p(x) = 1 ψ C (x C ) (9) Z where Z s some normalzaton constant. We can wrte ths n exponental famly form as: ( ) p(x) = exp ln ψ C (x C ) ln Z C If all the varables n the model have dscrete values, then for each clque C, we can defne an ndcator vector wth an entry for each confguraton of the varables n C. The suffcent statstc T (x) s formed by concatenatng the ndcator vectors for all the clques. In general, f each ψ C s an exponental famly dstrbuton, we can form T (x) by concatenatng the suffcent statstcs for these dstrbutons. In a drected graphcal model, we specfy a condtonal dstrbuton for each varable gven ts parents n the graph. The jont dstrbuton s: p(x) = p(x x π() ) (11) C (10)
6 6 Conjugacy and the Exponental Famly The exponental famly form of ths dstrbuton s smple: ( ) p(x) = exp ln p(x x π() ) (12) If each p(x x π() ) s an exponental famly dstrbuton, then t s clear that the dstrbuton n Eq. 12 s also n the exponental famly.
MATH 829: Introduction to Data Mining and Analysis The EM algorithm (part 2)
1/16 MATH 829: Introducton to Data Mnng and Analyss The EM algorthm (part 2) Domnque Gullot Departments of Mathematcal Scences Unversty of Delaware Aprl 20, 2016 Recall 2/16 We are gven ndependent observatons
More informationHidden Markov Models & The Multivariate Gaussian (10/26/04)
CS281A/Stat241A: Statstcal Learnng Theory Hdden Markov Models & The Multvarate Gaussan (10/26/04) Lecturer: Mchael I. Jordan Scrbes: Jonathan W. Hu 1 Hdden Markov Models As a bref revew, hdden Markov models
More informationUsing T.O.M to Estimate Parameter of distributions that have not Single Exponential Family
IOSR Journal of Mathematcs IOSR-JM) ISSN: 2278-5728. Volume 3, Issue 3 Sep-Oct. 202), PP 44-48 www.osrjournals.org Usng T.O.M to Estmate Parameter of dstrbutons that have not Sngle Exponental Famly Jubran
More informationEM and Structure Learning
EM and Structure Learnng Le Song Machne Learnng II: Advanced Topcs CSE 8803ML, Sprng 2012 Partally observed graphcal models Mxture Models N(μ 1, Σ 1 ) Z X N N(μ 2, Σ 2 ) 2 Gaussan mxture model Consder
More informationCS 2750 Machine Learning. Lecture 5. Density estimation. CS 2750 Machine Learning. Announcements
CS 750 Machne Learnng Lecture 5 Densty estmaton Mlos Hauskrecht mlos@cs.ptt.edu 539 Sennott Square CS 750 Machne Learnng Announcements Homework Due on Wednesday before the class Reports: hand n before
More informationStat260: Bayesian Modeling and Inference Lecture Date: February 22, Reference Priors
Stat60: Bayesan Modelng and Inference Lecture Date: February, 00 Reference Prors Lecturer: Mchael I. Jordan Scrbe: Steven Troxler and Wayne Lee In ths lecture, we assume that θ R; n hgher-dmensons, reference
More information8 : Learning in Fully Observed Markov Networks. 1 Why We Need to Learn Undirected Graphical Models. 2 Structural Learning for Completely Observed MRF
10-708: Probablstc Graphcal Models 10-708, Sprng 2014 8 : Learnng n Fully Observed Markov Networks Lecturer: Erc P. Xng Scrbes: Meng Song, L Zhou 1 Why We Need to Learn Undrected Graphcal Models In the
More informationThe EM Algorithm (Dempster, Laird, Rubin 1977) The missing data or incomplete data setting: ODL(φ;Y ) = [Y;φ] = [Y X,φ][X φ] = X
The EM Algorthm (Dempster, Lard, Rubn 1977 The mssng data or ncomplete data settng: An Observed Data Lkelhood (ODL that s a mxture or ntegral of Complete Data Lkelhoods (CDL. (1a ODL(;Y = [Y;] = [Y,][
More information3.1 Expectation of Functions of Several Random Variables. )' be a k-dimensional discrete or continuous random vector, with joint PMF p (, E X E X1 E X
Statstcs 1: Probablty Theory II 37 3 EPECTATION OF SEVERAL RANDOM VARIABLES As n Probablty Theory I, the nterest n most stuatons les not on the actual dstrbuton of a random vector, but rather on a number
More informationENG 8801/ Special Topics in Computer Engineering: Pattern Recognition. Memorial University of Newfoundland Pattern Recognition
EG 880/988 - Specal opcs n Computer Engneerng: Pattern Recognton Memoral Unversty of ewfoundland Pattern Recognton Lecture 7 May 3, 006 http://wwwengrmunca/~charlesr Offce Hours: uesdays hursdays 8:30-9:30
More informationMASSACHUSETTS INSTITUTE OF TECHNOLOGY 6.265/15.070J Fall 2013 Lecture 12 10/21/2013. Martingale Concentration Inequalities and Applications
MASSACHUSETTS INSTITUTE OF TECHNOLOGY 6.65/15.070J Fall 013 Lecture 1 10/1/013 Martngale Concentraton Inequaltes and Applcatons Content. 1. Exponental concentraton for martngales wth bounded ncrements.
More informationxp(x µ) = 0 p(x = 0 µ) + 1 p(x = 1 µ) = µ
CSE 455/555 Sprng 2013 Homework 7: Parametrc Technques Jason J. Corso Computer Scence and Engneerng SUY at Buffalo jcorso@buffalo.edu Solutons by Yngbo Zhou Ths assgnment does not need to be submtted and
More information2E Pattern Recognition Solutions to Introduction to Pattern Recognition, Chapter 2: Bayesian pattern classification
E395 - Pattern Recognton Solutons to Introducton to Pattern Recognton, Chapter : Bayesan pattern classfcaton Preface Ths document s a soluton manual for selected exercses from Introducton to Pattern Recognton
More informationGoodness of fit and Wilks theorem
DRAFT 0.0 Glen Cowan 3 June, 2013 Goodness of ft and Wlks theorem Suppose we model data y wth a lkelhood L(µ) that depends on a set of N parameters µ = (µ 1,...,µ N ). Defne the statstc t µ ln L(µ) L(ˆµ),
More informationProbabilistic Classification: Bayes Classifiers. Lecture 6:
Probablstc Classfcaton: Bayes Classfers Lecture : Classfcaton Models Sam Rowes January, Generatve model: p(x, y) = p(y)p(x y). p(y) are called class prors. p(x y) are called class condtonal feature dstrbutons.
More informationOutline. Bayesian Networks: Maximum Likelihood Estimation and Tree Structure Learning. Our Model and Data. Outline
Outlne Bayesan Networks: Maxmum Lkelhood Estmaton and Tree Structure Learnng Huzhen Yu janey.yu@cs.helsnk.f Dept. Computer Scence, Unv. of Helsnk Probablstc Models, Sprng, 200 Notces: I corrected a number
More informationGaussian process classification: a message-passing viewpoint
Gaussan process classfcaton: a message-passng vewpont Flpe Rodrgues fmpr@de.uc.pt November 014 Abstract The goal of ths short paper s to provde a message-passng vewpont of the Expectaton Propagaton EP
More informationComposite Hypotheses testing
Composte ypotheses testng In many hypothess testng problems there are many possble dstrbutons that can occur under each of the hypotheses. The output of the source s a set of parameters (ponts n a parameter
More informationParametric fractional imputation for missing data analysis. Jae Kwang Kim Survey Working Group Seminar March 29, 2010
Parametrc fractonal mputaton for mssng data analyss Jae Kwang Km Survey Workng Group Semnar March 29, 2010 1 Outlne Introducton Proposed method Fractonal mputaton Approxmaton Varance estmaton Multple mputaton
More informationMore metrics on cartesian products
More metrcs on cartesan products If (X, d ) are metrc spaces for 1 n, then n Secton II4 of the lecture notes we defned three metrcs on X whose underlyng topologes are the product topology The purpose of
More informationWeek 5: Neural Networks
Week 5: Neural Networks Instructor: Sergey Levne Neural Networks Summary In the prevous lecture, we saw how we can construct neural networks by extendng logstc regresson. Neural networks consst of multple
More informationDifferentiating Gaussian Processes
Dfferentatng Gaussan Processes Andrew McHutchon Aprl 17, 013 1 Frst Order Dervatve of the Posteror Mean The posteror mean of a GP s gven by, f = x, X KX, X 1 y x, X α 1 Only the x, X term depends on the
More informationHidden Markov Models
CM229S: Machne Learnng for Bonformatcs Lecture 12-05/05/2016 Hdden Markov Models Lecturer: Srram Sankararaman Scrbe: Akshay Dattatray Shnde Edted by: TBD 1 Introducton For a drected graph G we can wrte
More informationMaximum Likelihood Estimation of Binary Dependent Variables Models: Probit and Logit. 1. General Formulation of Binary Dependent Variables Models
ECO 452 -- OE 4: Probt and Logt Models ECO 452 -- OE 4 Maxmum Lkelhood Estmaton of Bnary Dependent Varables Models: Probt and Logt hs note demonstrates how to formulate bnary dependent varables models
More informationStatistics and Probability Theory in Civil, Surveying and Environmental Engineering
Statstcs and Probablty Theory n Cvl, Surveyng and Envronmental Engneerng Pro. Dr. Mchael Havbro Faber ETH Zurch, Swtzerland Contents o Todays Lecture Overvew o Uncertanty Modelng Random Varables - propertes
More informationLimited Dependent Variables
Lmted Dependent Varables. What f the left-hand sde varable s not a contnuous thng spread from mnus nfnty to plus nfnty? That s, gven a model = f (, β, ε, where a. s bounded below at zero, such as wages
More informationMachine learning: Density estimation
CS 70 Foundatons of AI Lecture 3 Machne learnng: ensty estmaton Mlos Hauskrecht mlos@cs.ptt.edu 539 Sennott Square ata: ensty estmaton {.. n} x a vector of attrbute values Objectve: estmate the model of
More informationSTATS 306B: Unsupervised Learning Spring Lecture 10 April 30
STATS 306B: Unsupervsed Learnng Sprng 2014 Lecture 10 Aprl 30 Lecturer: Lester Mackey Scrbe: Joey Arthur, Rakesh Achanta 10.1 Factor Analyss 10.1.1 Recap Recall the factor analyss (FA) model for lnear
More informationMaximum Likelihood Estimation (MLE)
Maxmum Lkelhood Estmaton (MLE) Ken Kreutz-Delgado (Nuno Vasconcelos) ECE 175A Wnter 01 UCSD Statstcal Learnng Goal: Gven a relatonshp between a feature vector x and a vector y, and d data samples (x,y
More informationANSWERS. Problem 1. and the moment generating function (mgf) by. defined for any real t. Use this to show that E( U) var( U)
Econ 413 Exam 13 H ANSWERS Settet er nndelt 9 deloppgaver, A,B,C, som alle anbefales å telle lkt for å gøre det ltt lettere å stå. Svar er gtt . Unfortunately, there s a prntng error n the hnt of
More informationThe Multiple Classical Linear Regression Model (CLRM): Specification and Assumptions. 1. Introduction
ECONOMICS 5* -- NOTE (Summary) ECON 5* -- NOTE The Multple Classcal Lnear Regresson Model (CLRM): Specfcaton and Assumptons. Introducton CLRM stands for the Classcal Lnear Regresson Model. The CLRM s also
More informationComputation of Higher Order Moments from Two Multinomial Overdispersion Likelihood Models
Computaton of Hgher Order Moments from Two Multnomal Overdsperson Lkelhood Models BY J. T. NEWCOMER, N. K. NEERCHAL Department of Mathematcs and Statstcs, Unversty of Maryland, Baltmore County, Baltmore,
More informationj) = 1 (note sigma notation) ii. Continuous random variable (e.g. Normal distribution) 1. density function: f ( x) 0 and f ( x) dx = 1
Random varables Measure of central tendences and varablty (means and varances) Jont densty functons and ndependence Measures of assocaton (covarance and correlaton) Interestng result Condtonal dstrbutons
More information3.1 ML and Empirical Distribution
67577 Intro. to Machne Learnng Fall semester, 2008/9 Lecture 3: Maxmum Lkelhood/ Maxmum Entropy Dualty Lecturer: Amnon Shashua Scrbe: Amnon Shashua 1 In the prevous lecture we defned the prncple of Maxmum
More informationMATH 5707 HOMEWORK 4 SOLUTIONS 2. 2 i 2p i E(X i ) + E(Xi 2 ) ä i=1. i=1
MATH 5707 HOMEWORK 4 SOLUTIONS CİHAN BAHRAN 1. Let v 1,..., v n R m, all lengths v are not larger than 1. Let p 1,..., p n [0, 1] be arbtrary and set w = p 1 v 1 + + p n v n. Then there exst ε 1,..., ε
More informationMaximum Likelihood Estimation
Maxmum Lkelhood Estmaton INFO-2301: Quanttatve Reasonng 2 Mchael Paul and Jordan Boyd-Graber MARCH 7, 2017 INFO-2301: Quanttatve Reasonng 2 Paul and Boyd-Graber Maxmum Lkelhood Estmaton 1 of 9 Why MLE?
More informationLecture Notes on Linear Regression
Lecture Notes on Lnear Regresson Feng L fl@sdueducn Shandong Unversty, Chna Lnear Regresson Problem In regresson problem, we am at predct a contnuous target value gven an nput feature vector We assume
More informationCIS526: Machine Learning Lecture 3 (Sept 16, 2003) Linear Regression. Preparation help: Xiaoying Huang. x 1 θ 1 output... θ M x M
CIS56: achne Learnng Lecture 3 (Sept 6, 003) Preparaton help: Xaoyng Huang Lnear Regresson Lnear regresson can be represented by a functonal form: f(; θ) = θ 0 0 +θ + + θ = θ = 0 ote: 0 s a dummy attrbute
More informationComputing MLE Bias Empirically
Computng MLE Bas Emprcally Kar Wa Lm Australan atonal Unversty January 3, 27 Abstract Ths note studes the bas arses from the MLE estmate of the rate parameter and the mean parameter of an exponental dstrbuton.
More informationStrong Markov property: Same assertion holds for stopping times τ.
Brownan moton Let X ={X t : t R + } be a real-valued stochastc process: a famlty of real random varables all defned on the same probablty space. Defne F t = nformaton avalable by observng the process up
More informationThe Geometry of Logit and Probit
The Geometry of Logt and Probt Ths short note s meant as a supplement to Chapters and 3 of Spatal Models of Parlamentary Votng and the notaton and reference to fgures n the text below s to those two chapters.
More informationMLE and Bayesian Estimation. Jie Tang Department of Computer Science & Technology Tsinghua University 2012
MLE and Bayesan Estmaton Je Tang Department of Computer Scence & Technology Tsnghua Unversty 01 1 Lnear Regresson? As the frst step, we need to decde how we re gong to represent the functon f. One example:
More informationMATH 281A: Homework #6
MATH 28A: Homework #6 Jongha Ryu Due date: November 8, 206 Problem. (Problem 2..2. Soluton. If X,..., X n Bern(p, then T = X s a complete suffcent statstc. Our target s g(p = p, and the nave guess suggested
More information1 (1 + ( )) = 1 8 ( ) = (c) Carrying out the Taylor expansion, in this case, the series truncates at second order:
68A Solutons to Exercses March 05 (a) Usng a Taylor expanson, and notng that n 0 for all n >, ( + ) ( + ( ) + ) We can t nvert / because there s no Taylor expanson around 0 Lets try to calculate the nverse
More informationClassification as a Regression Problem
Target varable y C C, C,, ; Classfcaton as a Regresson Problem { }, 3 L C K To treat classfcaton as a regresson problem we should transform the target y nto numercal values; The choce of numercal class
More informationOpen Systems: Chemical Potential and Partial Molar Quantities Chemical Potential
Open Systems: Chemcal Potental and Partal Molar Quanttes Chemcal Potental For closed systems, we have derved the followng relatonshps: du = TdS pdv dh = TdS + Vdp da = SdT pdv dg = VdP SdT For open systems,
More informationPHYS 705: Classical Mechanics. Calculus of Variations II
1 PHYS 705: Classcal Mechancs Calculus of Varatons II 2 Calculus of Varatons: Generalzaton (no constrant yet) Suppose now that F depends on several dependent varables : We need to fnd such that has a statonary
More informationLearning from Data 1 Naive Bayes
Learnng from Data 1 Nave Bayes Davd Barber dbarber@anc.ed.ac.uk course page : http://anc.ed.ac.uk/ dbarber/lfd1/lfd1.html c Davd Barber 2001, 2002 1 Learnng from Data 1 : c Davd Barber 2001,2002 2 1 Why
More informationModule 3: Element Properties Lecture 1: Natural Coordinates
Module 3: Element Propertes Lecture : Natural Coordnates Natural coordnate system s bascally a local coordnate system whch allows the specfcaton of a pont wthn the element by a set of dmensonless numbers
More informationLogistic Regression. CAP 5610: Machine Learning Instructor: Guo-Jun QI
Logstc Regresson CAP 561: achne Learnng Instructor: Guo-Jun QI Bayes Classfer: A Generatve model odel the posteror dstrbuton P(Y X) Estmate class-condtonal dstrbuton P(X Y) for each Y Estmate pror dstrbuton
More informationLecture 12: Classification
Lecture : Classfcaton g Dscrmnant functons g The optmal Bayes classfer g Quadratc classfers g Eucldean and Mahalanobs metrcs g K Nearest Neghbor Classfers Intellgent Sensor Systems Rcardo Guterrez-Osuna
More informationExpectation propagation
Expectaton propagaton Lloyd Ellott May 17, 2011 Suppose p(x) s a pdf and we have a factorzaton p(x) = 1 Z n f (x). (1) =1 Expectaton propagaton s an nference algorthm desgned to approxmate the factors
More informationMarkov Chain Monte Carlo (MCMC), Gibbs Sampling, Metropolis Algorithms, and Simulated Annealing Bioinformatics Course Supplement
Markov Chan Monte Carlo MCMC, Gbbs Samplng, Metropols Algorthms, and Smulated Annealng 2001 Bonformatcs Course Supplement SNU Bontellgence Lab http://bsnuackr/ Outlne! Markov Chan Monte Carlo MCMC! Metropols-Hastngs
More informationCanonical transformations
Canoncal transformatons November 23, 2014 Recall that we have defned a symplectc transformaton to be any lnear transformaton M A B leavng the symplectc form nvarant, Ω AB M A CM B DΩ CD Coordnate transformatons,
More information10-701/ Machine Learning, Fall 2005 Homework 3
10-701/15-781 Machne Learnng, Fall 2005 Homework 3 Out: 10/20/05 Due: begnnng of the class 11/01/05 Instructons Contact questons-10701@autonlaborg for queston Problem 1 Regresson and Cross-valdaton [40
More informationProf. Dr. I. Nasser Phys 630, T Aug-15 One_dimensional_Ising_Model
EXACT OE-DIMESIOAL ISIG MODEL The one-dmensonal Isng model conssts of a chan of spns, each spn nteractng only wth ts two nearest neghbors. The smple Isng problem n one dmenson can be solved drectly n several
More information8/25/17. Data Modeling. Data Modeling. Data Modeling. Patrice Koehl Department of Biological Sciences National University of Singapore
8/5/17 Data Modelng Patrce Koehl Department of Bologcal Scences atonal Unversty of Sngapore http://www.cs.ucdavs.edu/~koehl/teachng/bl59 koehl@cs.ucdavs.edu Data Modelng Ø Data Modelng: least squares Ø
More informationSupplementary material: Margin based PU Learning. Matrix Concentration Inequalities
Supplementary materal: Margn based PU Learnng We gve the complete proofs of Theorem and n Secton We frst ntroduce the well-known concentraton nequalty, so the covarance estmator can be bounded Then we
More informationComparison of the Population Variance Estimators. of 2-Parameter Exponential Distribution Based on. Multiple Criteria Decision Making Method
Appled Mathematcal Scences, Vol. 7, 0, no. 47, 07-0 HIARI Ltd, www.m-hkar.com Comparson of the Populaton Varance Estmators of -Parameter Exponental Dstrbuton Based on Multple Crtera Decson Makng Method
More informationProbabilistic & Unsupervised Learning
Probablstc & Unsupervsed Learnng Convex Algorthms n Approxmate Inference Yee Whye Teh ywteh@gatsby.ucl.ac.uk Gatsby Computatonal Neuroscence Unt Unversty College London Term 1, Autumn 2008 Convexty A convex
More informationLecture 3: Probability Distributions
Lecture 3: Probablty Dstrbutons Random Varables Let us begn by defnng a sample space as a set of outcomes from an experment. We denote ths by S. A random varable s a functon whch maps outcomes nto the
More informationπ e ax2 dx = x 2 e ax2 dx or x 3 e ax2 dx = 1 x 4 e ax2 dx = 3 π 8a 5/2 (a) We are considering the Maxwell velocity distribution function: 2πτ/m
Homework Solutons Problem In solvng ths problem, we wll need to calculate some moments of the Gaussan dstrbuton. The brute-force method s to ntegrate by parts but there s a nce trck. The followng ntegrals
More informationGeneralized Linear Methods
Generalzed Lnear Methods 1 Introducton In the Ensemble Methods the general dea s that usng a combnaton of several weak learner one could make a better learner. More formally, assume that we have a set
More informationEcon Statistical Properties of the OLS estimator. Sanjaya DeSilva
Econ 39 - Statstcal Propertes of the OLS estmator Sanjaya DeSlva September, 008 1 Overvew Recall that the true regresson model s Y = β 0 + β 1 X + u (1) Applyng the OLS method to a sample of data, we estmate
More informationEffects of Ignoring Correlations When Computing Sample Chi-Square. John W. Fowler February 26, 2012
Effects of Ignorng Correlatons When Computng Sample Ch-Square John W. Fowler February 6, 0 It can happen that ch-square must be computed for a sample whose elements are correlated to an unknown extent.
More informationEcon107 Applied Econometrics Topic 3: Classical Model (Studenmund, Chapter 4)
I. Classcal Assumptons Econ7 Appled Econometrcs Topc 3: Classcal Model (Studenmund, Chapter 4) We have defned OLS and studed some algebrac propertes of OLS. In ths topc we wll study statstcal propertes
More informationThe Basic Idea of EM
The Basc Idea of EM Janxn Wu LAMDA Group Natonal Key Lab for Novel Software Technology Nanjng Unversty, Chna wujx2001@gmal.com June 7, 2017 Contents 1 Introducton 1 2 GMM: A workng example 2 2.1 Gaussan
More informationAssortment Optimization under MNL
Assortment Optmzaton under MNL Haotan Song Aprl 30, 2017 1 Introducton The assortment optmzaton problem ams to fnd the revenue-maxmzng assortment of products to offer when the prces of products are fxed.
More informationRobert Eisberg Second edition CH 09 Multielectron atoms ground states and x-ray excitations
Quantum Physcs 量 理 Robert Esberg Second edton CH 09 Multelectron atoms ground states and x-ray exctatons 9-01 By gong through the procedure ndcated n the text, develop the tme-ndependent Schroednger equaton
More informationHomework Assignment 3 Due in class, Thursday October 15
Homework Assgnment 3 Due n class, Thursday October 15 SDS 383C Statstcal Modelng I 1 Rdge regresson and Lasso 1. Get the Prostrate cancer data from http://statweb.stanford.edu/~tbs/elemstatlearn/ datasets/prostate.data.
More informationThe conjugate prior to a Bernoulli is. A) Bernoulli B) Gaussian C) Beta D) none of the above
The conjugate pror to a Bernoull s A) Bernoull B) Gaussan C) Beta D) none of the above The conjugate pror to a Gaussan s A) Bernoull B) Gaussan C) Beta D) none of the above MAP estmates A) argmax θ p(θ
More informationTAIL BOUNDS FOR SUMS OF GEOMETRIC AND EXPONENTIAL VARIABLES
TAIL BOUNDS FOR SUMS OF GEOMETRIC AND EXPONENTIAL VARIABLES SVANTE JANSON Abstract. We gve explct bounds for the tal probabltes for sums of ndependent geometrc or exponental varables, possbly wth dfferent
More informationStatistical analysis using matlab. HY 439 Presented by: George Fortetsanakis
Statstcal analyss usng matlab HY 439 Presented by: George Fortetsanaks Roadmap Probablty dstrbutons Statstcal estmaton Fttng data to probablty dstrbutons Contnuous dstrbutons Contnuous random varable X
More informationSolutions Homework 4 March 5, 2018
1 Solutons Homework 4 March 5, 018 Soluton to Exercse 5.1.8: Let a IR be a translaton and c > 0 be a re-scalng. ˆb1 (cx + a) cx n + a (cx 1 + a) c x n x 1 cˆb 1 (x), whch shows ˆb 1 s locaton nvarant and
More informationMaximum Likelihood Estimation of Binary Dependent Variables Models: Probit and Logit. 1. General Formulation of Binary Dependent Variables Models
ECO 452 -- OE 4: Probt and Logt Models ECO 452 -- OE 4 Mamum Lkelhood Estmaton of Bnary Dependent Varables Models: Probt and Logt hs note demonstrates how to formulate bnary dependent varables models for
More information1 Motivation and Introduction
Instructor: Dr. Volkan Cevher EXPECTATION PROPAGATION September 30, 2008 Rce Unversty STAT 63 / ELEC 633: Graphcal Models Scrbes: Ahmad Beram Andrew Waters Matthew Nokleby Index terms: Approxmate nference,
More informationThe big picture. Outline
The bg pcture Vncent Claveau IRISA - CNRS, sldes from E. Kjak INSA Rennes Notatons classes: C = {ω = 1,.., C} tranng set S of sze m, composed of m ponts (x, ω ) per class ω representaton space: R d (=
More informationLINEAR REGRESSION ANALYSIS. MODULE IX Lecture Multicollinearity
LINEAR REGRESSION ANALYSIS MODULE IX Lecture - 30 Multcollnearty Dr. Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur 2 Remedes for multcollnearty Varous technques have
More informationChapter 8 Indicator Variables
Chapter 8 Indcator Varables In general, e explanatory varables n any regresson analyss are assumed to be quanttatve n nature. For example, e varables lke temperature, dstance, age etc. are quanttatve n
More informationThermodynamics and statistical mechanics in materials modelling II
Course MP3 Lecture 8/11/006 (JAE) Course MP3 Lecture 8/11/006 Thermodynamcs and statstcal mechancs n materals modellng II A bref résumé of the physcal concepts used n materals modellng Dr James Ellott.1
More informationProbabilistic & Unsupervised Learning. Introduction and Foundations
Probablstc & Unsupervsed Learnng Introducton and Foundatons Maneesh Sahan maneesh@gatsby.ucl.ac.uk Gatsby Computatonal Neuroscence Unt, and MSc ML/CSML, Dept Computer Scence Unversty College London Term
More informationNUMERICAL DIFFERENTIATION
NUMERICAL DIFFERENTIATION 1 Introducton Dfferentaton s a method to compute the rate at whch a dependent output y changes wth respect to the change n the ndependent nput x. Ths rate of change s called the
More informationError Probability for M Signals
Chapter 3 rror Probablty for M Sgnals In ths chapter we dscuss the error probablty n decdng whch of M sgnals was transmtted over an arbtrary channel. We assume the sgnals are represented by a set of orthonormal
More information1 Convex Optimization
Convex Optmzaton We wll consder convex optmzaton problems. Namely, mnmzaton problems where the objectve s convex (we assume no constrants for now). Such problems often arse n machne learnng. For example,
More informationP R. Lecture 4. Theory and Applications of Pattern Recognition. Dept. of Electrical and Computer Engineering /
Theory and Applcatons of Pattern Recognton 003, Rob Polkar, Rowan Unversty, Glassboro, NJ Lecture 4 Bayes Classfcaton Rule Dept. of Electrcal and Computer Engneerng 0909.40.0 / 0909.504.04 Theory & Applcatons
More informationRockefeller College University at Albany
Rockefeller College Unverst at Alban PAD 705 Handout: Maxmum Lkelhood Estmaton Orgnal b Davd A. Wse John F. Kenned School of Government, Harvard Unverst Modfcatons b R. Karl Rethemeer Up to ths pont n
More informationFeature Selection: Part 1
CSE 546: Machne Learnng Lecture 5 Feature Selecton: Part 1 Instructor: Sham Kakade 1 Regresson n the hgh dmensonal settng How do we learn when the number of features d s greater than the sample sze n?
More informationThe Feynman path integral
The Feynman path ntegral Aprl 3, 205 Hesenberg and Schrödnger pctures The Schrödnger wave functon places the tme dependence of a physcal system n the state, ψ, t, where the state s a vector n Hlbert space
More informationLectures - Week 4 Matrix norms, Conditioning, Vector Spaces, Linear Independence, Spanning sets and Basis, Null space and Range of a Matrix
Lectures - Week 4 Matrx norms, Condtonng, Vector Spaces, Lnear Independence, Spannng sets and Bass, Null space and Range of a Matrx Matrx Norms Now we turn to assocatng a number to each matrx. We could
More informationComplete subgraphs in multipartite graphs
Complete subgraphs n multpartte graphs FLORIAN PFENDER Unverstät Rostock, Insttut für Mathematk D-18057 Rostock, Germany Floran.Pfender@un-rostock.de Abstract Turán s Theorem states that every graph G
More informationGenerative classification models
CS 675 Intro to Machne Learnng Lecture Generatve classfcaton models Mlos Hauskrecht mlos@cs.ptt.edu 539 Sennott Square Data: D { d, d,.., dn} d, Classfcaton represents a dscrete class value Goal: learn
More informationLaboratory 3: Method of Least Squares
Laboratory 3: Method of Least Squares Introducton Consder the graph of expermental data n Fgure 1. In ths experment x s the ndependent varable and y the dependent varable. Clearly they are correlated wth
More informationBézier curves. Michael S. Floater. September 10, These notes provide an introduction to Bézier curves. i=0
Bézer curves Mchael S. Floater September 1, 215 These notes provde an ntroducton to Bézer curves. 1 Bernsten polynomals Recall that a real polynomal of a real varable x R, wth degree n, s a functon of
More informationConvergence of random processes
DS-GA 12 Lecture notes 6 Fall 216 Convergence of random processes 1 Introducton In these notes we study convergence of dscrete random processes. Ths allows to characterze phenomena such as the law of large
More informationLinear Regression Analysis: Terminology and Notation
ECON 35* -- Secton : Basc Concepts of Regresson Analyss (Page ) Lnear Regresson Analyss: Termnology and Notaton Consder the generc verson of the smple (two-varable) lnear regresson model. It s represented
More informationPredictive Analytics : QM901.1x Prof U Dinesh Kumar, IIMB. All Rights Reserved, Indian Institute of Management Bangalore
Sesson Outlne Introducton to classfcaton problems and dscrete choce models. Introducton to Logstcs Regresson. Logstc functon and Logt functon. Maxmum Lkelhood Estmator (MLE) for estmaton of LR parameters.
More informationb ), which stands for uniform distribution on the interval a x< b. = 0 elsewhere
Fall Analyss of Epermental Measurements B. Esensten/rev. S. Errede Some mportant probablty dstrbutons: Unform Bnomal Posson Gaussan/ormal The Unform dstrbuton s often called U( a, b ), hch stands for unform
More informationp(z) = 1 a e z/a 1(z 0) yi a i x (1/a) exp y i a i x a i=1 n i=1 (y i a i x) inf 1 (y Ax) inf Ax y (1 ν) y if A (1 ν) = 0 otherwise
Dustn Lennon Math 582 Convex Optmzaton Problems from Boy, Chapter 7 Problem 7.1 Solve the MLE problem when the nose s exponentally strbute wth ensty p(z = 1 a e z/a 1(z 0 The MLE s gven by the followng:
More informationLecture 4: September 12
36-755: Advanced Statstcal Theory Fall 016 Lecture 4: September 1 Lecturer: Alessandro Rnaldo Scrbe: Xao Hu Ta Note: LaTeX template courtesy of UC Berkeley EECS dept. Dsclamer: These notes have not been
More informationLecture 4 Hypothesis Testing
Lecture 4 Hypothess Testng We may wsh to test pror hypotheses about the coeffcents we estmate. We can use the estmates to test whether the data rejects our hypothess. An example mght be that we wsh to
More information