### ppt

```Probabilistic analog of clustering: mixture models
Pr(Xi ) = å r j Pr(Xi | q j )
j
Pr( j | Xi ) = rh Pr(Xi | q h ) / å r j Pr(Xi | q j )
j
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
multivariate normal distribution
Generalizing 2D correlation with a set of pairwise covariance
 – the covariance matrix || - det()
f (X) =
1
1
exp(- (x - m )T S-1 (x - m ))
2
2p k | S |
Multi-normality is a very strong restriction on data – although the model have
many – d2 - parameters and it is prone to sever over fitting
Restricting the covariance structure can be approached in many ways.
Expectation Maximization (EM)
(Working with e.g. a mixture of independent or correlated normal
distributions)
Initialize the mixture component parameters and mixture coefficients:
q1, r1
Compute the posterior probabilities: wij Pr(t =j|Xi)
Set new mixture coefficients: r2i=(1/m) j wij
Set new mixture components using weighted data wij, Xi
Iterate until convergence (no significant change in qlast, rlast)
Update mixture component using weight data – examples:
Independent normal: E(X[k]) E(X2[k]) is determined by weighted statistics
Full multivariate: all statistics (E(X[k]X[u]) is determined by weighted stats
Expectation-Maximization
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
Here t is ranging over all possible assignment of
log P(X | q ) = log å P(t, X | q )
the hidden mixture variable t per sample – so
t
km possibilities
P(t, X | q ) = P(t | X, q )P(X, q )
log P(X | q ) = logP(t, X | q ) - log P(t | X,q )
log P(X | q ) = å P(t | X,q k )log P(t, X | q ) - å P(t | X, q k )log P(t | X, q )
t
t
Q(q | q k ) = å P(t | X, q k )log P(t, X | q )
t
log P(X | q ) - log P(X | q k ) =
P(t | X, q k )
Q(q | q ) - Q(q | q ) + å P(t | X, q )log
P(t | X, q )
t
Relative entropy>=0
EM maximization
q k 1  arg maxQ(q | q k )
k
Dempster
q
k
k
k
(reminder: KL-divergence)
H ( P)   P( xi ) log P( xi )
i
1
1
max H ( P)   P( ) log P( )  log K
k
k
i
min H ( P)  0
Entropy (Shannon)
Shannon
H ( P || Q)   P( xi ) log
i
 H ( P ||| Q)   P( xi ) log
i
P( xi )
Q( xi )
Kullback-leibler divergence
 Q( xi ) 
Q( xi )
 P( xi )
 1  Q( xi )  P( xi )   0
P( xi ) i
 P( xi )  i
log(u)  u  1
H ( P || Q)  H (Q || P)
Not a metric!!
KL
Expectation-Maximization: Mixture model
æ
ö
k
Q(q | q ) = å P(t | X, q )log P(t, X | q ) = åç P(t | X, q )å log P(ti , Xi | q )÷
ø
t
t è
i
k
k
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).
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
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 search phrase history predict response to add
(Model within coherent user populations)
Multi-linear regression
Y=f(X) = Xb+e
Y – response variable
X – input variables
Goal: maximize LL(b,e) =logN(yi,m=f(xi),s)
Claim: least square is analogous to maximum likelihood
Pros: solution is easy
b=(XTX)-1XTy
RSS(b ) = (y - X b )T (y - X b )
= -2X T (y - X b ) = 0
¶b
Using QR decompoistion
X=QR where QTQ=I, R upper triangular:
B=(RTQTQR)-1RTQTy = (RTR)-1RTQTy=R-1QTy
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=Xb+e E(e|X)=0, V(e|X) = W (Omega must be estimated from the data)
We look for: b = argmin (Y-XbT W1(Y-Xb (e.g. multivariate normal density)
Solution obtained at: b = (XTW1X)-1XTW-1Y
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.
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 R2 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)
Using non-linear functions in linear
regression (generalized linear model)
We can add any function of X as a new auxiliary variable:
F(xi, log(xi), xi2)
we can add non linear interactions:
F(xi, xixj)
The linear assumption will take care of the efficient least square
process.
Using residual R2 can help determine which interactions are
useful/significant
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)
Cross validation
A model with significant R2 can be achieved by pure chance given many candidate
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.
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-Xb||2 + ||Gb||2
When gamma equals aI (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:
b=(XTX + GTG)-1XTy
(in the case of ridge regression, we simply add a constant to the diagonal of XTX)
Note the analogy of ridge regression and assuming a Bayesian normal prior
centered on 0 on the coefficients (paying ||Gb||2 in log probability)
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-Xb||2 + l1||b||
In particular, we can solve the standard least square problem under
the constraint of ||b||<t (a.k.a. the lasso). This is solved by
Shrinking the lasso and observing cross validation R^2 is routine.
It is also possible to combine ridge and lasso, a method nicknamed
elsatic net (this penalize very large coefficients, but also avoid many
small coefficients):
||Y-Xb||2 + l1||b||+l2||b||2
Discrete and non parametric modeling
Y=f(x1,x2) – 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
Parametric non-linear fitting
Y=f(x;a) – any function we know how to differentiate
c2=yi-yi(x;a))/si
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)
More on over fitting
Any type of analysis you are doing is a “test” – even if it is not a formal
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.
Train
Validation
Test
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?
```