time series
view markdownhighlevel
basics
 usually assume points are equally spaced
 modeling  for understanding underlying process or predicting
 nice blog, nice tutorial, Time Series for scikitlearn People
 noise, seasonality (regular / predictable fluctuations), trend, cycle
 multiplicative models: time series = trend * seasonality * noise
 additive model: time series = trend + seasonality + noise
 stationarity  mean, variance, and autocorrelation structure do not change over time
 endogenous variable = x = independent variable
 exogenous variable = y = dependent variable
libraries
 pandas has some great timeseries functionality
 skits library for forecasting
highlevel modelling
 common methods
 decomposition  identify each of these components given a timeseries
 ex. loess, exponential smoothing
 frequencybased methods  e.g. look at spectral plot
 (AR) autoregressive models  linear regression of current value of one or more prior values of the series
 (MA) movingaverage models  require fitting the noise terms
 (ARMA) boxjenkins approach
 decomposition  identify each of these components given a timeseries
 moving averages
 simple moving average  just average over a window
 cumulative moving average  mean is calculated using previous mean
 exponential moving average  exponentially weights up more recent points
 prediction (forecasting) models
 autoregressive integrated moving average (arima)
 assumptions: stationary model
 autoregressive integrated moving average (arima)
similarity measures
 An Empirical Evaluation of Similarity Measures for Time Series Classification (serra et al. 2014)
 lockstep measures (Euclidean distance, or any norm)
 can resample to make them same length
 featurebased measures (Fourier coefficients)
 euclidean distance over all coefs is same as over timeseries, but we usually filter out highfreq coefs
 can also use wavelets
 modelbased measures (autoregressive)
 compare coefs of an AR (or ARMA) model
 elastic measures
 dynamic time warping = DTW  optimallt aligns in temporal domaub ti nubunuze accumulated cost
 can also enforce some local window around points
 Every index from the first sequence must be matched with one or more indices from the other sequence and vice versa
 The first index from the first sequence must be matched with the first index from the other sequence (but it does not have to be its only match)
 The last index from the first sequence must be matched with the last index from the other sequence (but it does not have to be its only match)
 The mapping of the indices from the first sequence to indices from the other sequence must be monotonically increasing, and vice versa, i.e. if
j > i
are indices from the first sequence, then there must not be two indicesl > k
in the other sequence, such that indexi
is matched with indexl
and indexj
is matched with indexk
, and vice versa
 edit distance EDR
 timewarped edit distance  TWED
 minimum jump cost  MJC
 dynamic time warping = DTW  optimallt aligns in temporal domaub ti nubunuze accumulated cost
 lockstep measures (Euclidean distance, or any norm)
book1 (A course in Time Series Analysis) + book2 (Intro to Time Series and Forecasting)
ch 1
 when errors are dependent, very hard to distinguish noise from signal
 usually in timeseries analysis, we begin by detrending the data and analyzing the residuals
 ex. assume linear trend or quadratic trend and subtract that fit (or could include sin / cos for seasonal behavior)
 ex. look at the differences instead of the points (nth order difference removes nth order polynomial trend). However, taking differences can introduce dependencies in the data
 ex. remove trend using sliding window (maybe with exponential weighting)
 periodogram  in FFT, this looks at the magnitude of the coefficients (but loses the phase information)
ch 2  stationary time series
 in time series, we never get iid data
 instead we make assumptions
 ex. the process has a constant mean (a type of stationarity)
 ex. the dependencies in the timeseries are shortterm
 autocorrelation plots: plot correlation of series vs series offset by different lags
 formal definitions of stationarity for time series ${X_t}$
 strict stationarity  the distribution is the same across time
 secondorder / weak stationarity  mean is constant for all t and, for any t and k, the covariance between $X_t$ and $X_{t+k}$ only depends on the lag difference k
 In other words, there exists a function $c: \mathbb Z \to \mathbb R$ such that for all t and k we have $c(k) = \text{cov} (X_t, X_{t+k})$

strict stationary and $E X_T^2 < \infty \implies$ secondorder stationary
 ergodic  stronger condition, says samples approach the expectation of functions on the time series: for any function $g$ and shift $\tau_1, … \tau_k$:
 $\frac 1 n \sum_t g(X_t, … X_{t+\tau_k}) \to \mathbb E [g(X_0, …, X_{t+\tau_k} )]$
 causal  can predict given only past values (for Gaussian processes no difference)
ch 3  linear time series
note: can just assume all have 0 mean (otherwise add a constant)
 AR model $AR(p)$: \(X_t = \sum_{i=1}^p \phi_i X_{ti}+ \varepsilon_t\)
 $\phi_1, \ldots, \phi_p$ are parameters
 $\varepsilon_t$ is white noise

stationary assumption places constraints on param values (e.g. processes in the $AR(1)$ model with $ \phi_1 \ge 1$ are not stationary)  looks just like linear regression, but is more complex
 if we don’t account for issues, things can go wrong
 model will not be stationary
 model may be misspecified

$E(\epsilon_t X_{tp}) \neq 0$
 this represents a set of difference equations, and as such, must have a solution
 if we don’t account for issues, things can go wrong

ex. $AR(1)$ model  if $ \phi < 0$, then soln is in terms of past values of {$\epsilon_t$}, otherwise it is in terms of future values  ex. simulating  if we know $\phi$ and ${\epsilon_t}$, we still need to use the backshift operator to solve for ${ X_t }$

ex. $AR(p)$ model  if $\sum_j \phi_j $< 1, and $\mathbb E \epsilon_t < \infty$, then will have a causal stationary solution  backshift operator $B^kX_t=X_{tk}$
 solving requires using the backshift operator, because we need to solve for what all the residuals are
 characteristic polynomial $\phi(a) = 1  \sum_{j=1}^p \phi_j a^j$
 $\phi(B) X_t = \epsilon_t$
 $X_t=\phi(B)^{1} \epsilon_t$
 can represent $AR(p)$ as a vector $AR(1)$ using the vector $\bar X_t = (X_t, …, X_{tp+1})$
 note: can reparametrize in terms of frequencies
 MA model $MA(q)$: $ X_t = \sum_{i=1}^q \theta_i \varepsilon_{ti} + \varepsilon_t$
 $\theta_1 … \theta_q$ are params
 $\varepsilon_t$, $\varepsilon_{t1}$ are white noise error terms
 harder to fit, because the lagged error terms are not visible (also means can’t make preds on new timeseries)
 $E[\epsilon_t] = 0$, $Var[\epsilon_t] = 1$
 much harder to estimate these parameters
 $X_t = \theta (B) \epsilon_t$ (assuming $\theta_0=1$)
 ARMA model: $ARMA(p, q)$: $X_t = \sum_{i=1}^p \phi_i X_{ti} + \sum_{i=1}^q \theta_i \varepsilon_{ti} + \varepsilon_t$
 ${X_t}$ is stationary
 $\phi (B) X_t = \theta(B) \varepsilon_t$
 $\phi(B) = 1  \sum_{j=1}^p \phi_j B^j$
 $\theta(B) = 1 + \sum_{j=1}^{q}\theta_jz^j$
 causal if $\exists { \psi_j }$ such that $X_t = \sum_{j=0}^\infty \psi_j Z_{tj}$ for all t
 ARIMA model: $ARIMA(p, d, q)$:  generalizes ARMA model to nonstationarity (using differencing)
ch 4 + 8  the autocovariance function + parameter estimation
 estimation
 pure autoregressive
 Yulewalker
 Burg estimation  minimizing sums of squares of forward and backward onestep prediction errors with respect to the coefficients
 when $q > 0$
 innovations algorithm
 hannanrissanen algorithm
 pure autoregressive
 autocovariance function: {$\gamma(k): k \in \mathbb Z$} where $\gamma(k) = \text{Cov}(X_{t+h}. X_t) = \mathbb E (X_0 X_k)$ (assuming mean 0)
 YuleWalker equations (assuming AR(p) process): $\mathbb E (X_t X_{tk}) = \sum_{j=1}^p \phi_j \mathbb E (X_{tj} X_{tk}) + \underbrace{\mathbb E (\epsilon_tX_{tk})}{=0} = \sum{j=1}^p \phi_j \mathbb E (X_{tj} X_{tk})$
 ex. MA covariance becomes 0 with lag > num params

can rewrite the YuleWalker equations
 $\gamma(i) = \sum_{j=1}^p \phi_j \gamma(i j)$
 $\underline\gamma_p = \Gamma_p \underline \phi_p$
 $(\Gamma_p)_{i, j} = \gamma(i  j)$
 $\hat{\Gamma}_p$ is nonegative definite (and nonsingular if there is at least one nonzero $Y_i$)
 $\underline \gamma_p = [\gamma(1), …, \gamma(p)]$
 $\underline \phi_p = (\phi_1, …, \phi_p)$
 this minimizes the mse $\mathbb E [X_{t+1}  \sum_{j=1}^p \phi_j X_{t+1j}]^2$
 use estimates to solve: $\hat{\underline \phi}_p = \hat \Sigma_p^{1} \hat{\underline r}_p $
 the innovations algorithm
 set $\hat X_1 = 0$
 innovations = onestep prediction errors $U_n = X_n  \hat X _n$
 mle (ch 5.2)
 eq. 5.2.9: Gaussian likelihood for an ARMA process
 $r_n = \mathbb E[(W_{n+1}  \hat W_{n+1})^2]$
multivariate timeseries ch 7
 vectorvalued timeseries has dependencies between variables across time
 just modeling as univariate fails to take into account possible dependencies between the series