diff --git a/lectures/lectures/data/fig/bias_good.png b/lectures/lectures/data/fig/bias_good.png
new file mode 100644
index 0000000..ff20048
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diff --git a/lectures/lectures/data/fig/bias_variance.png b/lectures/lectures/data/fig/bias_variance.png
new file mode 100644
index 0000000..c28d225
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diff --git a/lectures/lectures/dynamics.html b/lectures/lectures/dynamics.html
index 6635c8e..085d395 100644
--- a/lectures/lectures/dynamics.html
+++ b/lectures/lectures/dynamics.html
@@ -496,7 +496,7 @@
Fixed Points for Linear Functions
eigvals, eigvecs = eig(A)
print (f"lambda_1= { eigvals[0 ]} , ||x* - A x*||= { norm(A @ eigvecs[:,0 ] - eigvecs[:,0 ])} " )
-
lambda_1=(1+0j), ||x* - A x*||=1.5700924586837752e-16
+
lambda_1=(1+0j), ||x* - A x*||=1.1102230246251565e-16
diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-10-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-10-output-1.png
index 1f72e10..814e2b0 100644
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diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-12-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-12-output-1.png
index 08ba60c..f00fb29 100644
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diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-14-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-14-output-1.png
index ba9218e..1df721e 100644
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diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-4-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-4-output-1.png
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diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-7-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-7-output-1.png
index ebb840d..b25f5ab 100644
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diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-8-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-8-output-1.png
index 0295bda..a7cca46 100644
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diff --git a/lectures/lectures/dynamics_files/figure-revealjs/cell-9-output-1.png b/lectures/lectures/dynamics_files/figure-revealjs/cell-9-output-1.png
index c0bd645..1813409 100644
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diff --git a/lectures/lectures/eigenvalue_applications.html b/lectures/lectures/eigenvalue_applications.html
index fa79c0e..0f7f29f 100644
--- a/lectures/lectures/eigenvalue_applications.html
+++ b/lectures/lectures/eigenvalue_applications.html
@@ -512,7 +512,7 @@ Iterating with \(\rho(A) > 1\)
rho(A) = 1.079128784747792
-x_200 = [3406689.32410674 6102361.18640517]
+x_200 = [3406689.32410673 6102361.18640516]
@@ -556,7 +556,7 @@ Iterating with \(\rho(A) = 1\)
print (f"x_ { t} = { np. linalg. matrix_power(A, t) @ x_0} " )
check orthogonal: dot(x_1,x_2) approx 0: 0.0
-rho(A) = 1.0000000000000002
+rho(A) = 1.0
x_200 = [ 0.27639321 -0.17082039]
@@ -803,7 +803,7 @@ Condition Numbers of Matrices
print (f"condition(A) = { cond(A)} , condition(A^(-1)) = { cond(inv(A))} " )
condition(I) = 1.0
-condition(A) = 40000001.939191714, condition(A^(-1)) = 40000002.00307444
+condition(A) = 40000001.962777555, condition(A^(-1)) = 40000002.02779216
@@ -859,8 +859,8 @@ Solving an Example
error using inv(A) = { norm(A @ c_inv - y, np.inf)} " )
print (f"cond(A) = { cond(A)} " )
-
error = 5.820766091346741e-11, error using inv(A) = 1.3387762010097504e-09
-cond(A) = 564652.3214074654
+
error = 1.574562702444382e-11, error using inv(A) = 1.1932570487260818e-09
+cond(A) = 564652.3214000753
@@ -877,8 +877,8 @@ Things Getting Poorly Conditioned Quickly
error using inv(A) = { norm(A @ c_inv - y, np.inf)} " )
print (f"cond(A) = { cond(A)} " )
-
error = 1.280568540096283e-09, error using inv(A) = 6.463262252509594e-06
-cond(A) = 4462817558043.969
+
error = 5.334186425898224e-10, error using inv(A) = 6.22717197984457e-06
+cond(A) = 4462824600234.486
@@ -895,8 +895,8 @@ Matrix Inverses Fail Completely for \(N = 20\)error using inv(A) = { norm(A @ c_inv - y, np.inf)} " )
print (f"cond(A) = { cond(A):.4g} " )
-
error = 5.820766091346741e-10, error using inv(A) = 2460.8631448635133
-cond(A) = 5.771e+24
+
error = 6.784830475226045e-10, error using inv(A) = 31732.823760853855
+cond(A) = 1.697e+24
@@ -917,7 +917,7 @@ Moral of this Story
A_monomial = np.array([[x_i** n for n in range (N + 1 )] for x_i in x]) # or np.vander
print (f"cond(A) = { cond(A):.4g} , cond(A_monomial) = { cond(A_monomial):.4g} " )
-
cond(A) = 3.64e+09, cond(A_monomial) = 1.694e+17
+
cond(A) = 3.64e+09, cond(A_monomial) = 2.926e+18
diff --git a/lectures/lectures/eigenvalue_applications_files/figure-revealjs/cell-11-output-1.png b/lectures/lectures/eigenvalue_applications_files/figure-revealjs/cell-11-output-1.png
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diff --git a/lectures/lectures/eigenvalue_applications_files/figure-revealjs/cell-8-output-1.png b/lectures/lectures/eigenvalue_applications_files/figure-revealjs/cell-8-output-1.png
index 0c5b73c..2ecf8f6 100644
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diff --git a/lectures/lectures/index.html b/lectures/lectures/index.html
index 9daada2..f9b3f06 100644
--- a/lectures/lectures/index.html
+++ b/lectures/lectures/index.html
@@ -136,6 +136,7 @@ Lectures
Probability, Conditioning, and Independence , Jupyter , PDF
Stochastic Processes , Jupyter , PDF
Intro to Causality , Jupyter , PDF
+Uncertainty Quantification in Applied Economics , Jupyter , PDF
diff --git a/lectures/lectures/introduction_to_causality.html b/lectures/lectures/introduction_to_causality.html
index f4abef8..3e1fa49 100644
--- a/lectures/lectures/introduction_to_causality.html
+++ b/lectures/lectures/introduction_to_causality.html
@@ -1061,19 +1061,6 @@ Estimating Treatment Effects Without Randomization
Estimating Treatment Effects Without Randomization
-
-Many identification assumptions are based on the idea of selection on observables
-
-This means that the treatment assignment is independent of the potential outcomes conditional on the observed covariates
-In other words, \(Y_0\) and \(Y_1\) are independent of \(T\) conditional on \(X\)
-
-This allows us to do things like match units in the treatment and control groups that are similar on average
-
-We can then estimate the treatment effect by comparing the outcomes of the matched units, assuming that the matched units are similar on average
-
-Another option is to use instrumental variables to estimate the treatment effect
-Alternatively, a structural model can be used to estimate the treatment effect by integrating a theoretical model to fill in the missing counterfactuals
-
Singular Values (sqrt eigenvalues):
-[25.0823 1.0254 0.6468]
+[21.5216 0.8732 0.7096]
Explained Variance (ordered):
-[0.9977 0.0017 0.0007]
+[0.9973 0.0016 0.0011]
@@ -626,8 +626,8 @@ Dimension Reduction with PCA
print (f"Correlation of Z_1 to Z_hat_1 = { np. corrcoef(Z.T, Z_hat.T)[0 ,2 ]} " )
print (f"Correlation of Z_2 to Z_hat_2 = { np. corrcoef(Z.T, Z_hat.T)[1 ,3 ]} " )
-
Correlation of Z_1 to Z_hat_1 = 0.9989685407197146
-Correlation of Z_2 to Z_hat_2 = -0.622136330126575
+
Correlation of Z_1 to Z_hat_1 = 0.9987396670122092
+Correlation of Z_2 to Z_hat_2 = -0.6413512732572132
@@ -813,7 +813,7 @@ Plotting Code with Seaborn
plt.show()
-
+
@@ -832,7 +832,7 @@ k-means to Recover the Latent Groups
corr = df["k" ].corr(df["k_hat" ])
print (f"Correlation between k and k_hat: { corr:.2f} " )
-
Correlation between k and k_hat:-0.83
+
Correlation between k and k_hat:-0.93
@@ -870,7 +870,7 @@ Potentially Swap \(\hat{k}\) and Compare if x['k' ] == x['k_hat' ] else r'$k \neq \hat {k} $' ,
axis= 1 )
-
Correlation now 0.8300415031127608
+
Correlation now 0.9300465034877902
@@ -886,7 +886,7 @@ Plotting the Uncovered Latent Groups
plt.show()
-
+
@@ -945,7 +945,7 @@ Digging Deeper
Lambda, Q = eig(A)
print (np.real(Lambda))
-
[ 1.10000000e+00 -2.65486721e-09]
+
[ 1.10000000e+00 -2.65486733e-09]
@@ -968,7 +968,7 @@ Evolution Matrix is Very Simple with \(\lambda_2 =
q_1_inv = np.reshape(inv(Q)[0 ,:], (1 ,2 ))
norm(A - lambda_1 * q_1 @ q_1_inv) # pretty close to zero!
-
2.663274529925679e-09
+
2.663274500543771e-09
@@ -998,7 +998,7 @@ Implementation
print (f"norm = { norm(d[:,1 :] - d_hat)} " )
y_hat = G @ d_hat
-
norm = 2.3494397540428033e-10
+
norm = 2.3494410875961204e-10
Let’s see if these line up perfectly
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index 389112a..3924a1e 100644
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index b253a54..649fb80 100644
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index 252cfd8..eca2dbb 100644
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diff --git a/lectures/lectures/linear_algebra_foundations.html b/lectures/lectures/linear_algebra_foundations.html
index 04b9edc..32196a6 100644
--- a/lectures/lectures/linear_algebra_foundations.html
+++ b/lectures/lectures/linear_algebra_foundations.html
@@ -1121,9 +1121,9 @@ Example of LLS using Scipy
print (f"beta = \n { beta} \n beta_hat = \n { beta_hat} " )
beta =
- [-0.81011697 0.47576408 -0.08064125 -0.21201846 -1.02869662]
+ [ 1.27699654 1.24976206 -0.02314793 -0.1603755 -1.71006662]
beta_hat =
-[-0.81519622 0.47790174 -0.08893845 -0.21818441 -1.02778959]
+[ 1.26798224 1.24374081 -0.02376603 -0.16370129 -1.72027267]
@@ -1135,9 +1135,9 @@ Solving using the Normal Equations
print (f"beta = \n { beta} \n beta_hat = \n { beta_hat} " )
beta =
- [-0.81011697 0.47576408 -0.08064125 -0.21201846 -1.02869662]
+ [ 1.27699654 1.24976206 -0.02314793 -0.1603755 -1.71006662]
beta_hat =
-[-0.81519622 0.47790174 -0.08893845 -0.21818441 -1.02778959]
+[ 1.26798224 1.24374081 -0.02376603 -0.16370129 -1.72027267]
@@ -1165,7 +1165,7 @@ Collinearity and Estimation
print (f"cond(X'*X)= { cond(X.T@ X)} , cond(X_col'*X_col)= { cond(X_col.T@ X_col)} " )
-
cond(X'*X)=2819.3329786399063, cond(X_col'*X_col)=1.2999933999712892e+16
+
cond(X'*X)=2819.332978639814, cond(X_col'*X_col)=1.1014450683078442e+16
diff --git a/lectures/lectures/probability.html b/lectures/lectures/probability.html
index a2cec1f..1d9a169 100644
--- a/lectures/lectures/probability.html
+++ b/lectures/lectures/probability.html
@@ -666,7 +666,7 @@ Using the discrete_rv
E(X) = 34500.0
E(f(X)) = 182.2474487139159
CDF(X) = [0.2 1. 0.1]
-Samples of X = [40000 15000 40000 40000 40000]
+Samples of X = [40000 40000 10000 40000 40000]
@@ -729,7 +729,7 @@ The Binomial Distribution
Mean: 5.00
Variance: 2.50
-Draws of u: [3 5 5 6 6]
+Draws of u: [3 5 7 8 3]
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index c3cd825..6d84619 100644
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diff --git a/lectures/lectures/stochastic_processes.html b/lectures/lectures/stochastic_processes.html
index ebcd0fe..f353586 100644
--- a/lectures/lectures/stochastic_processes.html
+++ b/lectures/lectures/stochastic_processes.html
@@ -640,7 +640,7 @@ Implementation in Python
plt.plot(X.T)
-
+
@@ -729,7 +729,7 @@ Simulating Unit Root
Visualizing the Distribution of Many Trajectories
-
+
@@ -976,7 +976,7 @@ Coding Markov Chain in Python
X_0 = 0, X_1 = 0
X_t indices =
- [0 0 0 0 0 0 0 0 0 0 0]
+ [0 1 1 1 1 1 1 1 1 1 1]
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+
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+ ECON 526 Lectures - ECON526: Quantitative Economics with Data Science Applications
+
+
+
+
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+ ECON526: Quantitative Economics with Data Science Applications
+ Uncertainty Quantification in Applied Economics
+
+
+
+
+Phil Solimine
+
+
+
+ University of British Columbia
+
+
+
+
+
+
+Table of contents
+
+
+
+
+
+
+Summary
+
+Last class, we covered the meaning of causal effects and some of the challenges of estimating them from observational data.
+Today, we will discuss how we measure the uncertainty associated with our estimates of causal effects.
+We will also introduce the bias-variance tradeoff and how it relates to the uncertainty of our estimates.
+
+
+
+
+
+Bias
+
+Remember that the bias of an estimator is the difference between the expected value of the estimator and the true value of the parameter we are trying to estimate.
+There are a number of types of bias that can arise in our estimators.
+In causal inference, we are often interested in the ATE or ATT.
+
+Much of the discussion of bias in causal inference is focused on the bias of estimators of these quantities.
+The estimator we are usually concerned about is the difference in sample means between the treatment and control groups.
+This particular bias is given by the formula \(E[Y\mid T=1] - E[Y\mid T=0] = \text{ATT} + E[Y_0\mid T=1] - E[Y_0\mid T=0]\)
+
+
+
+
+Bias
+
+Some types of bias are due to the fact that we are using an estimator that is not the best one for the parameter we are trying to estimate.
+
+These types of bias can often be fixed by getting more data, or by tweaking the estimator itself.
+For example, while \(\hat{\sigma}^2 = \frac{1}{n}\sum_{i=1}^{n} (x-\bar{x})^2\) seems like a natural estimator for the variance of a random variable \(x\) , it’s expected value is actually \(E[\hat{\sigma}^2]=\frac{n-1}{n}\sigma^2 = \sigma^2 - \frac{1}{n}\sigma^2\leftarrow \text{(bias)}\) .
+We can fix this by using \(\frac{1}{n-1}\sum_{i=1}^n (x-\bar{x})^2\) instead. (The Bessel correction)
+Note that \(\lim_{n\rightarrow \infty} \frac{1}{n} = 0\) , so this bias term vanishes as we get more data. This type of estimator is called consistent .
+
+
+
+
+Bias
+
+Now look back at the formula \[
+ E[Y\mid T=1] - E[Y\mid T=0] = \text{ATT} + \underbrace{E[Y_0\mid T=1] - E[Y_0\mid T=0]}_{\text{bias}}
+ \]
+Notice that there is nothing about this bias term that will force it to go to zero as we get more data.
+These types of bias, like omitted variable bias , and selection bias are more due to the fact that we are ignoring some important aspect of the data-generating process, therefore they can’t be fixed by simply getting more data.
+
+
+
+
+
+Standard Errors
+
+Usually the estimators we study are based on sample averages of random variables.
+
+If we don’t have a lot of data, and the data-generating process has a lot of variation, then our sample average will be very sensitive to the particular sample we draw.
+As we get more data, the sample average will be closer to the true mean and less sensitive to the particular sample we draw.
+
+The equation for the standard error of a sample average is: \(\text{SE} = \frac{\sigma}{\sqrt{n}}\)
+
+Where \(\sigma\) is the standard deviation of the random variable and \(n\) is our sample size.
+This is called Moivre’s equation
+
+
+
+
+
+
+Standard Errors
+
+The standard error of a sample average is a measure of the uncertainty of our estimate of the true mean.
+To see why this might be important, let’s look at an example.
+For this, we will use a dataset that contains ENEM scores for students in Brazil, from different schools, over a three year time period.
+
+
+
df = pd.read_csv("./data/enem_scores.csv" )
+ df.sort_values(by= "avg_score" , ascending= False ).head(5 )
+
+
+
+
+
+
+
+
+
+
+16670
+2007
+33062633
+68
+82.97
+
+
+16796
+2007
+33065403
+172
+82.04
+
+
+16668
+2005
+33062633
+59
+81.89
+
+
+16794
+2005
+33065403
+177
+81.66
+
+
+10043
+2007
+29342880
+43
+80.32
+
+
+
+
+
+
+
+
+
+Standard Errors - Example
+
+We want to discover if there is a relationship between school quality and student performance.
+As a first step, let’s split out the top 1% of schools by average score, and compare the number of students in those schools to the number of students in the rest of the schools.
+
+
+
+
plot_data = (df
+ .assign(top_school = df["avg_score" ] >= np.quantile(df["avg_score" ], .99 ))
+ [["top_school" , "number_of_students" ]]
+ .query(f"number_of_students< { np. quantile(df['number_of_students' ], .98 )} " )) # remove outliers
+
+ plt.figure(figsize= (3 ,3 ))
+ sns.boxplot(x= "top_school" , y= "number_of_students" , data= plot_data)
+ plt.title("Number of Students of 1% Top Schools (Right)" );
+
+
+
+
+
+
+
+
+Standard Errors - Example
+
+
+
+
+
+
+We can see that the top 1% of schools have a lot fewer students than the rest of the schools.
+This might lead us to draw some conclusions, like “smaller schools are better”.
+
+
+
+Standard Errors - Example
+
+Now let’s take a look at the full distribution of scores by school size.
+
+
+
+
q_99 = np.quantile(df["avg_score" ], .99 )
+ q_01 = np.quantile(df["avg_score" ], .01 )
+
+ plot_data = (df
+ .sample(10000 )
+ .assign(Group = lambda d: np.select([d["avg_score" ] > q_99, d["avg_score" ] < q_01],
+ ["Top" , "Bottom" ], "Middle" )))
+ plt.figure(figsize= (5 ,5 ))
+ sns.scatterplot(y= "avg_score" , x= "number_of_students" , hue= "Group" , data= plot_data)
+ plt.title("ENEM Score by Number of Students" );
+
+
+
+
+
+
+
+
+Standard Errors - Example
+
+
+
+
+
+
+This captures exactly what we would expect if there was no relationship between school size and student performance.
+Our false conclusion is a direct result of the formula \(\text{SE} = \frac{\sigma}{\sqrt{n}}\) .
+Since each observation in our dataset is a sample average , the schools with a lot of students give very precise estimates of the true mean, while the schools with fewer students give noisier estimates.
+
+
+
+
+Example: An Evaluation of Online Learning
+
+
+
+Standard Errors in a Causal Context
+
+Let’s return to causal inference.
+We will explore the following data, which contain the results of an RCT that randomized students into online and face-to-face sections of a course.
+This dataset contains observations of 323 students who were randomized into three different class formats. It comes from:
+
+Alpert et al. 2016 AER . A Randomized Assessment of Online Learning.
+
+
+
+
+
+
+
+
+
+
+
+
+
+0
+0
+0.0
+0.0
+0.0
+0.0
+0.0
+1.0
+0
+0.0
+63.29997
+
+
+1
+1
+0.0
+0.0
+0.0
+0.0
+0.0
+1.0
+0
+0.0
+79.96000
+
+
+2
+1
+0.0
+0.0
+0.0
+0.0
+0.0
+1.0
+0
+1.0
+83.37000
+
+
+
+
+
+
+
+
+
+Standard Errors in a Causal Context
+
+Since these data come from an RCT, we can estimate the ATE by simply comparing the average scores of the different treatment groups.
+
+
+
(data
+ .assign(class_format = np.select(
+ [data["format_ol" ].astype(bool ), data["format_blended" ].astype(bool )],
+ ["online" , "blended" ],
+ default= "face_to_face"
+ ))
+ .groupby(["class_format" ])
+ .mean())
+
+
+
+
+
+
+
+
+class_format
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+blended
+0.550459
+0.217949
+0.102564
+0.025641
+0.012821
+0.012821
+0.628205
+0.0
+1.0
+77.093731
+
+
+face_to_face
+0.633333
+0.202020
+0.070707
+0.000000
+0.010101
+0.000000
+0.717172
+0.0
+0.0
+78.547485
+
+
+online
+0.542553
+0.228571
+0.028571
+0.014286
+0.028571
+0.000000
+0.700000
+1.0
+0.0
+73.635263
+
+
+
+
+
+
+
+
+
+Standard Errors in a Causal Context
+
+
+
+
+
+
+
+
+
+class_format
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+blended
+0.550459
+0.217949
+0.102564
+0.025641
+0.012821
+0.012821
+0.628205
+0.0
+1.0
+77.093731
+
+
+face_to_face
+0.633333
+0.202020
+0.070707
+0.000000
+0.010101
+0.000000
+0.717172
+0.0
+0.0
+78.547485
+
+
+online
+0.542553
+0.228571
+0.028571
+0.014286
+0.028571
+0.000000
+0.700000
+1.0
+0.0
+73.635263
+
+
+
+
+
+
+
+
+For reference, the averages of these variables are:
+
+
+
+
+
+
+
+
+
+
+
+
+0
+0.578947
+0.214575
+0.068826
+0.012146
+0.016194
+0.004049
+0.684211
+0.291022
+0.337461
+76.627336
+
+
+
+
+
+
+
+
+
+Standard Errors in a Causal Context
+
+Now let’s take a closer look at the average scores by treatment group.
+
+
+
+
exam_scores = (data
+ .assign(class_format = np.select(
+ [data["format_ol" ].astype(bool ), data["format_blended" ].astype(bool )],
+ ["online" , "blended" ],
+ default= "face_to_face"
+ ))
+ .groupby(["class_format" ])
+ .mean())["falsexam" ]
+ exam_scores
+
+
+
class_format
+blended 77.093731
+face_to_face 78.547485
+online 73.635263
+Name: falsexam, dtype: float64
+
+
+
+
+Since these data come from an RCT, we can estimate the ATE by simply comparing the average scores of the different treatment groups, relative to the control group (face-to-face).
+
+
+
+
print (f"Online format changed test scores by { (exam_scores['online' ] - exam_scores['face_to_face' ]):.4} points." )
+print (f"Blended format changed test scores by { (exam_scores['blended' ] - exam_scores['face_to_face' ]):.4} points." )
+
+
+
Online format changed test scores by -4.912 points.
+Blended format changed test scores by -1.454 points.
+
+
+
+
+
+Standard Errors in a Causal Context
+
+Online format decreased test scores by almost 5 points, while the blended format decreased test scores by almost 2 points.
+
+Relative to the face-to-face format.
+
+But because of the relatively small sample, there’s a chance that our estimates are wrong.
+
+We can use the standard error of the sample average to quantify the uncertainty of our estimates.
+Having a low standard error (relative to the size of the effect) gives us more confidence that the estimate is correct.
+
+
+
+
+
online = data.query("format_ol==1" )["falsexam" ]
+ face_to_face = data.query("format_ol==0 & format_blended==0" )["falsexam" ]
+def se(y: pd.Series):
+ return y.std() / np.sqrt(len (y))
+
+print (f"SE for Online: { se(online):.3} points" )
+print (f"SE for Face to Face: { se(face_to_face):.3} points" )
+
+
+
SE for Online: 1.54 points
+SE for Face to Face: 0.872 points
+
+
+
+
+
+
+Confidence Intervals
+
+
+
+Confidence Intervals
+
+We can use the standard error of the sample average to construct a confidence interval around our estimate.
+A confidence interval is a range of values that we are confident contains the true value of the parameter we are trying to estimate.
+The confidence interval is constructed by taking the sample average and adding and subtracting a multiple of the standard error.
+
+The multiple we use is determined by how confident we want to be that the true value is in the interval.
+If the estimator takes a normal distribution, then we can use the quantiles of the normal distribution to determine the multiple.
+
+
+
+
+Confidence Intervals
+
+Let’s suppose we have a true abstract distribution of students’ test scores to better grasp this.
+Imagine it is a normal distribution with a true mean of 74 and a true standard deviation of 2.
+We can simulate a sample of 500 students from this distribution and calculate the sample average.
+
+
+
+
def run_experiment():
+ return np.random.normal(74 , 2 , 500 )
+
+ np.random.seed(42 )
+
+ plt.figure(figsize= (8 ,2.5 ))
+ freq, bins, img = plt.hist([run_experiment().mean() for _ in range (10000 )], bins= 40 , label= "Experiment Means" )
+ plt.vlines(74 , ymin= 0 , ymax= freq.max (), linestyles= "dashed" , label= "True Mean" , color= "orange" )
+ plt.legend();
+
+
+
+
+
+
+
+
+Aside: Central Limit Theorem
+
+Let’s try the same thing, but with the data coming from a uniform distribution.
+
+
+
+
def run_experiment_unif():
+ return np.random.uniform(64 , 84 , 500 )
+
+ np.random.seed(42 )
+
+ plt.figure(figsize= (8 ,2.5 ))
+ freq, bins, img = plt.hist([run_experiment_unif().mean() for _ in range (10000 )], bins= 40 , label= "Experiment Means" )
+ plt.vlines(74 , ymin= 0 , ymax= freq.max (), linestyles= "dashed" , label= "True Mean" , color= "orange" )
+ plt.legend();
+
+
+
+
+
+
+
+In fact, the central limit theorem tells us that the sample average of any * distribution will be normally distributed as the sample size gets large.
+
+*As long as the mean and variance of the distribution are finite.
+
+
+
+
+Confidence Intervals
+
+Of course, usually we won’t have the luxury of simulating our experiment thousands of times to get a sense of the distribution of our estimator.
+But we can use the CLT, and the approximate normality of the sample mean, to construct a confidence interval around our estimate.
+Confidence intervals are coupled with a probability (usually 90%, 95%, or 99%).
+
+This probability tells us the percentage of times that we would expect an experiment to produce an estimate within the interval.
+
+
+
+
+Confidence Intervals
+
+These confidence intervals would look something like this:
+
+
+
+
np.random.seed(321 )
+ exp_data = run_experiment()
+ exp_se = exp_data.std() / np.sqrt(len (exp_data))
+ exp_mu = exp_data.mean()
+ ci = (exp_mu - 2 * exp_se, exp_mu + 2 * exp_se)
+print (ci)
+ x = np.linspace(exp_mu - 4 * exp_se, exp_mu + 4 * exp_se, 100 )
+ y = stats.norm.pdf(x, exp_mu, exp_se)
+ plt.plot(x, y, color= "orange" )
+ plt.vlines(ci[1 ], ymin= 0 , ymax= 1 )
+ plt.vlines(ci[0 ], ymin= 0 , ymax= 1 , label= "95% CI" )
+ plt.legend()
+ plt.show()
+
+
+
(73.82718114045632, 74.17341543460314)
+
+
+
+
+
+
+
+
+Confidence Intervals
+
+Back to our classroom experiment, we can construct the confidence interval for the mean exam score in both online and face-to-face formats.
+
+
+
+
def ci(y: pd.Series):
+ return (y.mean() - 2 * se(y), y.mean() + 2 * se(y))
+
+print ("95% CI for Online:" , ci(online))
+print ("95 % f or Face to Face:" , ci(face_to_face))
+
+
+
95% CI for Online: (70.56094429049804, 76.7095818797147)
+95% for Face to Face: (76.80278229206951, 80.29218687459715)
+
+
+
+
+Not only are the means different, but the confidence intervals also do not overlap.
+
+This gives us a good amount of certainty that online format actually does decrease test scores.
+
+
+
+
+Confidence Intervals
+
+Without confidence intervals, point estimates are not very useful.
+
+We can’t tell if the difference between the means is due to chance or not.
+We can’t tell if the difference is large or small.
+Therefore some measure of uncertainty should always be reported along with the point estimate.
+
+A common mistake is to interpret the confidence interval as the probability that the true value is in the interval.
+
+This is not technically correct.
+The true value is either in the interval or it is not.
+Really, the confidence interval should be interpreted as the frequency with which the interval would contain the true value, if the experiment were repeated many times.
+
+
+
+
+
+
+Hypothesis Testing
+
+Another way to quantify the uncertainty of our estimates is to use hypothesis testing .
+
+Is the difference in means statistically different from zero (or some other value)?
+
+Recall that the sum or difference of two independent normal random variables is also normally distributed.
+
+Therefore, we can use the CLT to construct a test statistic that is normally distributed.
+
+The resulting mean will be the sum or difference between the two distributions, while the variance will always be the sum of the variance:
+
+\(N(\mu_1, \sigma_1^2) - N(\mu_2, \sigma_2^2) = N(\mu_1 - \mu_2, \sigma_1^2 + \sigma_2^2)\)
+\(N(\mu_1, \sigma_1^2) + N(\mu_2, \sigma_2^2) = N(\mu_1 + \mu_2, \sigma_1^2 + \sigma_2^2)\)
+
+
+
+
+Hypothesis Testing
+
+Hypothesis testing is another way to quantify the uncertainty of our estimates.
+
+It is very closely related to confidence intervals.
+
+If we have two normal distributions, and want to test if the difference between the means is zero, we can construct a test statistic that is normally distributed.
+
+\(\mu_{diff} = \mu_1 - \mu_2\)
+\(SE_{diff} = \sqrt{\sigma_1^2/n_1 + \sigma_2^2/n_2}\)
+
+
+
+
+Hypothesis Testing
+
+Returning to our classroom experiment, we can construct a hypothesis test to determine if the difference in means is different from zero.
+The null hypothesis is that the difference in means is zero.
+
+\(H_0: \mu_{online} - \mu_{face-to-face} = 0\)
+
+The alternative hypothesis is that the difference in means is not zero.
+
+\(H_1: \mu_{online} - \mu_{face-to-face} \neq 0\)
+
+Notice that the alternative hypothesis is not that the difference is positive or negative .
+
+This is because we are using a two-sided test.
+We are testing if the difference is different from zero, not if it is greater or less than zero.
+Also, notice that the hypotheses are mutually exclusive and collectively exhaustive.
+
+
+
+
+Hypothesis Testing
+
+
diff_mu = online.mean() - face_to_face.mean()
+ diff_se = np.sqrt(face_to_face.var()/ len (face_to_face) + online.var()/ len (online))
+ ci = (diff_mu - 1.96 * diff_se, diff_mu + 1.96 * diff_se)
+print (ci)
+
+
(-8.376410208363385, -1.4480327880905248)
+
+
+
+
+
x = np.linspace(diff_mu - 4 * diff_se, diff_mu + 4 * diff_se, 100 )
+ y = stats.norm.pdf(x, diff_mu, diff_se)
+ plt.plot(x, y)
+ plt.vlines(ci[1 ], ymin= 0 , ymax= .05 )
+ plt.vlines(ci[0 ], ymin= 0 , ymax= .05 , label= "95% CI" )
+ plt.legend()
+ plt.show()
+
+
+
+
+
+
+
+
+Hypothesis Testing
+
+Based on the results, we can see that based on our original standard errors, we are 95% confident that the true difference in means is between -8.37 and -1.63.
+Therefore, we can reject the null hypothesis that the difference in means is zero, at the 5% level.
+Alternatively, we can say that the difference in means is statistically significant at the 5% level .
+
+
+
+Hypothesis Testing
+
+We can also construct a z-statistic to test the null hypothesis.
+
+\(z = \frac{\mu_{diff} - H_0}{SE_{diff}} = \frac{\mu_1 - \mu_2 -0 }{\sqrt{\sigma_1^2/n_1 + \sigma_2^2/n_2}}\)
+
+The z-statistic is the number of standard errors that the difference in means is from the null hypothesis.
+Under the null hypothesis, the z-statistic is normally distributed with mean zero and variance one.
+
+Therefore, we can simply calculate the z-statistic and compare it to the quantiles of the normal distribution to determine if the difference in means is statistically significant.
+
+
+
+
+
+P-Values
+
+With all of the previous methods, we have been able to answer yes-or-no questions about our estimates.
+
+Is the difference in means statistically different from zero at the 95% level?
+Is the difference in means statistically significant at the 5% level?
+
+However, a more useful question might be how different are the means?
+
+Is the difference in means large or small?
+Is the difference in means practically significant?
+
+To answer these questions, we can use p-values .
+
+
+
+P-Values
+
+The p-value is the probability of observing a test (z) statistic at least as extreme as the one we calculate, if the null hypothesis is true .
+P-values allow us to quantify uncertainty without needing to specify a confidence level.
+
+We can simply report the p-value and let the reader decide what level of uncertainty they are comfortable with.
+
+The p-value is calculated by taking the area under the normal distribution curve that is more extreme than the test statistic.
+
+The p-values is not the probability that the null hypothesis is true (\(P(H_0)\mid data\) ).
+Instead it is the probability of observing the data, under the null (\(P(data)\mid H_0\) ).
+
+
+
+
+P-Values
+
+Let’s calculate the p-value for our classroom experiment.
+
+
+
z = diff_mu / diff_se
+ p_value = 2 * (1 - stats.norm.cdf(z))
+print (f"z-statistic: { z:.3} " )
+print (f"p-value: { p_value:.3} " )
+
+
z-statistic: -2.78
+p-value: 1.99
+
+
+
+The p-value of 0.0027 tells us that we can reject the null hypothesis at the 5% level.
+
+The difference in means is statistically significant at the 5% level. (The 95% confidence interval does not contain zero.)
+In fact, we could reject the null hypothesis at the 1% level as well. (The 99% confidence interval does not contain zero.)
+However, we could not reject the null hypothesis at the 0.1% (or 0.2%) level. (The 99.9% confidence interval does contain zero.)
+
+
+
+
+
+The Bias-Variance Tradeoff
+
+
+
+The Bias-Variance Tradeoff
+
+The bias-variance tradeoff is a fundamental concept in statistics and machine learning.
+There is a often a tradeoff between the bias and variance of an estimator.
+
+An estimator with low bias will have high variance.
+An estimator with low variance will have high bias.
+
+While we generally want to minimize both bias and variance, it can often be the case that introducing a little bias will reduce the variance of the estimator by a large amount.
+
+
+
+The Bias-Variance Tradeoff
+
+Let’s look at an example.
+Rembember our first example of a biased estimator, the sample variance.
+The simple sample variance (without the Bessel correction) is biased because \(E[\frac{1}{n} \sum_{i=1}^n (x_i - \bar{x})^2] = \frac{n-1}{n}\sigma^2\) .
+
+The bias term is \(\frac{1}{n}\sigma^2\) .
+
+For an unbiased estimator, we simply need to replace \(\frac{1}{n}\) with \(\frac{1}{n-1}\) .
+
+This gets rid of the bias term, and it is still consistent (since the difference between \(\frac{1}{n}\) and \(\frac{1}{n-1}\) goes to zero as \(n\) gets large).
+
+
+
+
+The Bias-Variance Tradeoff
+
+Let’s consider instead the whole class of estimators of the form \(\hat{\sigma}_c^2 = c \sum_{i=1}^n (x_i - \bar{x})^2\) .
+
+The simple sample variance is the special case where \(c = \frac{1}{n}\) .
+The unbiased sample variance is the special case where \(c = \frac{1}{n-1}\) .
+
+Remember that \(E[\hat{\sigma}_\frac{1}{n}^2] = \frac{n-1}{n}\sigma^2\) .
+
+The bias term is \(\frac{1}{n}\sigma^2\) .
+We can use the linearity of expectation to calculate the bias of any estimator of this form.
+\(E[\hat{\sigma}_c^2] = c (n-1) \sigma^2\) .
+
+Therefore, in order to minimize the bias, we need to choose \(c = \frac{1}{n-1}\) .
+
+
+
+The Bias-Variance Tradeoff
+
+However, we can also calculate the variance of this estimator.
+
+\(Var(\hat{\sigma}_c^2) = 2c^2 \sigma^4 (n-1)\)
+
+Instead of finding the value of \(c\) that minimizes the bias, we can find the value of \(c\) that minimizes the variance (MSE) of the estimator.
+
+\(MSE(\hat{\sigma}^2_c) = E[(\hat{\sigma}_c^2 - \sigma^2)^2] = E[\hat{\sigma}_c^2 - \sigma^2]^2 + Var(\hat{\sigma}_c^2)\)
+(\(Var(\hat{\sigma}_c^2)\) is the variance of the estimator, or the square of its standard error.)
+Plugging in our formula for the variance, \(MSE(\hat{\sigma}^2_c) = (c(n-1)-1)^2 \sigma^4 + 2c^2 \sigma^4 (n-1)\) .
+
+If we wanted to minimize the standard error of the estimate, instead of the bias, minimizing this standard error would actually lead us to choose \(c = \frac{1}{n+1}\) .
+
+
+
+The Bias-Variance Tradeoff
+
+Let’s plot the bias and variance of the estimator for different values of \(c\) .
+
+
+
+
def bias_sq(c,sigma= 5 ,n= 10 ):
+ return (c * (n- 1 )- 1 )** 2 * sigma** 4
+
+def mse(c,sigma= 5 ,n= 10 ):
+ return (c* (n- 1 )- 1 )** 2 * sigma** 4 + 2 * c** 2 * sigma** 4 * (n- 1 )
+
+ n = 10
+ sigma = 5
+ c = np.linspace(0 , 0.2 , 100 )
+ plt.plot(c, bias_sq(c), label= "Bias Squared" )
+ plt.plot(c, mse(c), label= "MSE" , color = "red" )
+ plt.vlines(1 / (n- 1 ), ymin= 0 , ymax= 800 , linestyles= "dashed" , label= "1/(n-1)" )
+ plt.vlines(1 / (n+ 1 ), ymin= 0 , ymax= 800 , linestyles= "dashed" , color = "red" , label= "1/(n+1)" )
+
+ plt.legend()
+ plt.show()
+
+
+
+
+
+
+
+
+The Bias-Variance Tradeoff
+
+Source: https://en.wikipedia.org/wiki/Bias_of_an_estimator
+
+The Bias-Variance Tradeoff
+
+
+Source: https://www.shiksha.com/online-courses/articles/bias-and-variance/
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
+
\ No newline at end of file
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