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Probabilistic analog of clustering: mixture models We model uncertainty in the identification of objects to mixture components Each mixture component can.

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Presentation on theme: "Probabilistic analog of clustering: mixture models We model uncertainty in the identification of objects to mixture components Each mixture component can."— Presentation transcript:

1 Probabilistic analog of clustering: mixture models We model uncertainty in the identification of objects to mixture components Each mixture component can be based on some appropriate model -Independent discrete (binomial,multinormial) -Independent normals -Mutlivariate normals -More complex dependency model (e.g. Tree, Bayesian network, Markov Random Field…) This is our first model with a hidden variable T->X or P(T,X) = P(T)*P(X|T) The probability of the data is derived by marginalization over the hidden variables

2 multivariate normal distribution Generalizing 2D correlation with a set of pairwise covariance  – the covariance matrix |  | - det(  ) Multi-normality is a very strong restriction on data – although the model have many – d 2 - parameters and it is prone to sever over fitting Restricting the covariance structure can be approached in many ways.

3 Expectation Maximization (EM) (Working with e.g. a mixture of independent or correlated normal distributions) Initialize the mixture component parameters and mixture coefficients:  1,  1 Compute the posterior probabilities: w ij Pr(t =j|X i ) Set new mixture coefficients:  2 i =(1/m)  j w ij Set new mixture components using weighted data w ij, X i Iterate until convergence (no significant change in  last,  last ) Update mixture component using weight data – examples: Independent normal: E(X[k]) E(X 2 [k]) is determined by weighted statistics Full multivariate: all statistics (E(X[k]X[u]) is determined by weighted stats

4 Expectation-Maximization Relative entropy>=0 EM maximization Dempster The most important property of the EM algorithm is that it is guaranteed to improve the likelihood of the data. This DOES NOT MEAN it will find a good solution. Bad initialization will converge to bad outcome. Here t is ranging over all possible assignment of the hidden mixture variable t per sample – so k m possibilities

5 (reminder: KL-divergence) Entropy (Shannon) Kullback-leibler divergence KL Shannon Not a metric!!

6 Expectation-Maximization: Mixture model Q can be brought back to the form of a sum over independent terms, k of them depends only on the parameters of one mixture component, and one depends on the mixture coefficient. Maximization of each of these component can then be shown to be done as in the non-mixture case (e.g. using the empirical covariance matrix for the multi-normal distribution).

7 Multi-dimensional data: Analysis vs. modeling Cases/experiments (n) X Features/Variables (m) Clustering one dimension to k behaviors: -km parameters using means only -km*2 parameters using mean/variance -K[m+m*(m-1)/2] full covariance matrix for each cluster.. Why modeling? -Further reducing the number of parameters -Extracting meaningful model parameters, features, dependency -> out ultimate goal as analysts What we are not going to do here: -Classification -Black box regression As analysts this is typically less attractive to us. It is by far more prone to experimental and other biases

8 Examples again (explained in class) Gene expression of single cells (cells/genes) Regulating genes predict regulated genes in cells (model within coherent cell populations) Patients/medical record Various clinical factors predict hypertension (model within coherent patient populations) User records in google (user/(search->ad->hit)) User search phrase history predict response to add (Model within coherent user populations)

9 Multi-linear regression Y=f(X) = X  +  Y – response variable X – input variables Goal: minimize RSS=  (y i -f(x i )) 2 (or ||Y-X  || 2 ) Goal: maximize LL( ,  ) =  logN(y i,  =f(x i ),  ) Claim: least square is analogous to maximum likelihood Pros: solution is easy  =(X T X) -1 X T y Using QR decompoistion X=QR where Q T Q=I, R upper triangular: B=(R T Q T QR) -1 R T Q T y = (R T R) -1 R T Q T y=R -1 Q T y

10 Multilinear modeling - relaxing some assumptions 0. Inputs are non-degenerate (but this is easy to correct) 1. Noise on responses in uncorrelated with the mean (homoscedasticity) Can be corrected by a. Weighted least square b. non linear transformation of the response (e.g. log(y), or In general y/stdev(y|x)) 2. Noise on responses is independent Generalized least square: Y=X  +  E(  |X)=0, V(  |X) =  (Omega must be estimated from the data) We look for:  = argmin (Y-X     (Y-X  (e.g. multivariate normal density) Solution obtained at:  = (X T   X) -1 X T W -1 Y 3. No noise on the inputs This is more of a pain. Require some type of inference on the inputs. No guarantee model is well defined or identifiable. Discussed in class.

11 Testing model fit and components Linear fitting will always find the optimal solution But this solution can be completely, or partially meaningless Global metrics: The R 2 of the entire model The coefficient of each variable can be interpreted directly by computing its T-value as in Pearson correlation analysis We can test a model omitting a variable and compute the differential R^2 or the correlation of the hidden variable and the residual response) But - adding many insignificant variables will always increase the fit : (schematic graphs showed in class)

12 Using non-linear functions in linear regression (generalized linear model) We can add any function of X as a new auxiliary variable: F(x i, log(x i ), x i 2 ) we can add non linear interactions: F(x i, x i x j ) The linear assumption will take care of the efficient least square process. Using residual R 2 can help determine which interactions are useful/significant

13 Testing subsets; Greedy approaches Given a large number of potential input variables, we can try to find the best subset of variables such that all of them a residually significant a)Start from all the variables and eliminate iteratively the worst variable b)Start from the highest correlation variable and iteratively add the variable with highest correlation to the residual c)Do any local optimization (Adding and removing variables)

14 Cross validation A model with significant R 2 can be achieved by pure chance given many candidate inputs and inadequate sample size A robust procedure for controlling such over fitting is cross validation 1. Divide the data into k parts For each i: 2. Fit the data while omitting the data in the ith part 3. Compute the performance of the resulting model on the hidden data The resulting cross validation R^2 should be reasonably similar to the one obtained when working on all the data. You can draw a graph showing reduction in cross validation fit given various modeling decisions In particular, when you divide a dataset of n cases into n parts the procedure is called leave-one-out cross validation. Not covered here: Akaike information criterion (AIC), Bayesian information criterion (BIC) and other theoretically founded tools for model selection.

15 Ridge/Tikhonov regression To control over-fitting when using a large number input variables, we can add a regularization component to the regression goal function: ||Y-X  || 2 + ||  || 2 When gamma equals  I (the unit matrix times alpha), this is called ridge regression, and set a fixed penalty on non-zero coefficients. Gamma can also encode smoothing constraints such as when using a difference operator. This is useful if the input variable are assumed to represent related effects. Conveniently, the solution to the Tikhonov regression is still explicit:  =(X T X +  T  ) -1 X T y (in the case of ridge regression, we simply add a constant to the diagonal of X T X) Note the analogy of ridge regression and assuming a Bayesian normal prior centered on 0 on the coefficients (paying ||  || 2 in log probability)

16 Lasso and Elastic net regression Instead of Gaussian priors on the coefficient, we may wish to penalize coefficients linearly. This will give more weight to eliminating small coefficients, and will be less troubled by having few strong coefficients: ||Y-X  || ||  || In particular, we can solve the standard least square problem under the constraint of ||  ||

17 Discrete and non parametric modeling Y=f(x 1,x 2 ) – but the functional form is very unclear On the other hand, there is a lot of data We can discretize x1,x2 and study the table (y|bin1,bin2). (for example, y can be normally distributed within each bin). (or, y can be a linear function of x1,x2 in each bin) This a-parametric approach lose power since each bin is treated independently. But if a dataset is extensive, this may not be a problem. It is not easily scalable to many inputs, unless some parametric assumptions can be used

18 Parametric non-linear fitting Y=f(x;a) – any function we know how to differentiate  2 =  y i -y i (x;a))/  i Important: we know how to compute the gradient and hessian of the function Minimization is done using a combination of gradient descent and solution to the local linear least square problem (Levenberg-Marquardt method)

19 More on over fitting Train Validation Test Any type of analysis you are doing is a “test” – even if it is not a formal part of your multiple testing When building models, avoid testing irrelevant hypotheses – anything you looked at is “burnt”. Instead, perform inclusive descriptive analysis that is not making specific hypotheses (e.g. clustering, or any top-down approach) Keep some of the data for final testing, or perform follow ups.

20 Accurate modeling does not imply causality A variable can predict other variables because of indirect, non causal relation A->B->C can be transformed to C->B->A (how? Compute!) How can we infer causality: Perturbation/interventions (experiments) Time separation More?


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