Paper Trail #10: Generalized Autoregressive Conditional Heteroskedasticity (Bollerslev, 1986) — the paper that gave us GARCH(1,1)
Bollerslev (1986) extends Engle’s 1982 ARCH by letting the current conditional variance depend on past conditional variances as well as past squared errors. The result — GARCH(1,1), h_t = α_0 + α_1 · ε²_(t−1) + β_1 · h_(t−1)— became the workhorse volatility model for the next 40 years and gave macro and FX quants a two-parameter alternative to Engle & Kraft’s hand-tuned ARCH(8) lag structures. Verified against the full 21-page PDF Bollerslev hosts on his Duke faculty page.
The paper, in one sentence
“A natural generalization of the ARCH (Autoregressive Conditional Heteroskedastic) process introduced in Engle (1982) to allow for past conditional variances in the current conditional variance equation is proposed. Stationarity conditions and autocorrelation structure for this new class of parametric models are derived. Maximum likelihood estimation and testing are also considered. Finally an empirical example relating to the uncertainty of the inflation rate is presented.” That’s the abstract, verbatim from page 307. The paper proceeds in seven sections; the memorable one is Section 7, the empirical head-to-head against Engle & Kraft’s (1983) ARCH(8) US-inflation model.
The GARCH(p, q) definition
For a real-valued discrete-time process ε_t with information set ψ_(t−1) at time t−1, Bollerslev defines (eq. 1-2 of the paper, verbatim from page 309):
ε_t | ψ_(t−1) ~ N(0, h_t)
h_t = α_0 + Σ_(i=1..q) α_i · ε²_(t−i) + Σ_(i=1..p) β_i · h_(t−i)
with α_0 > 0, α_i ≥ 0 for i=1..q, and β_i ≥ 0for i=1..p. When p=0 the process collapses to Engle’s ARCH(q). When p=q=0 ε_t is simply white noise. The parametric form is deliberately symmetric to the ARMA(p,q) generalization of the standard AR(p) process, and Bollerslev argues in the introduction that this symmetry is the main reason GARCH is easier to identify from an autocorrelation function than ad-hoc-lagged ARCH is.
Stationarity condition (Theorem 1)
Verbatim from page 310: “The GARCH(p, q) process as defined in (1) and (2) is wide-sense stationary with E(ε_t) = 0, var(ε_t) = α_0 / (1 − A(1) − B(1)), and cov(ε_t, ε_s) = 0 for t ≠ s if and only if A(1) + B(1) < 1.” In the GARCH(1,1) special case this simplifies to α_1 + β_1 < 1— which Bollerslev’s empirical fit meets at 0.135 + 0.829 = 0.964, close to the unit-root boundary but on the stationary side.
The empirical example: US inflation, 1948-1983
Bollerslev picks Engle & Kraft’s (1983) US inflation model as the head-to-head comparison. Data: π_t = 100 · ln(GD_t / GD_(t−1)) where GD_t is the US GNP implicit price deflator, taken from the Citibank Economic Database and the September 1984 Survey of Current Business. Quarterly, 1948.Q2 to 1983.Q4, 143 observations. OLS with heteroskedastic-consistent standard errors.
Engle & Kraft’s ARCH(8) fit(verified from eq. 30 of Bollerslev’s paper):
π_t = 0.138 + 0.423 π_(t−1) + 0.222 π_(t−2) + 0.377 π_(t−3) − 0.175 π_(t−4) + ε_t
h_t = 0.058 + 0.802 · Σ_(i=1..8) (9−i)/36 · ε²_(t−i)
Bollerslev’s alternative GARCH(1,1) fit (verified from eq. 31):
π_t = 0.141 + 0.433 π_(t−1) + 0.229 π_(t−2) + 0.349 π_(t−3) − 0.162 π_(t−4) + ε_t
h_t = 0.007 + 0.135 · ε²_(t−1) + 0.829 · h_(t−1)
Diagnostic comparison, verbatim from the paper
| Model | Kurtosis | Skew | Mean lag (variance eq) | Median lag |
|---|---|---|---|---|
| OLS (eq. 29) | 6.90 | −0.13 | n/a | n/a |
| ARCH(8) (eq. 30) | 4.07 | +0.18 | 3.500 (forced) | 2.500 |
| GARCH(1,1) (eq. 31) | 3.81 | +0.11 | 5.848 | 3.696 |
The normal target for kurtosis is 3.00. All three skewness estimates are within one asymptotic standard error of zero (√(6/T) = 0.20) — the fits are approximately symmetric. The kurtosis progression 6.90 → 4.07 → 3.81 is the headline: the plain OLS residuals are heavily leptokurtic, ARCH(8) pulls them significantly closer to normal, and GARCH(1,1) pulls them closer still with fewer parameters. Bollerslev also runs LM tests for adding a GARCH(1,2) or GARCH(2,1) term (statistic 3.80, not significant at 5%) and for adding ε²_(t−2) through ε²_(t−5) directly (5.58, the 0.77 fractile of χ² — not significant). The GARCH(1,1) form isn’t just parsimonious; it’s statistically hard to improve.
Why FX traders should care
Two reasons. First, GARCH is what quantifies the volatility clustering that shows up when you compute the autocorrelation of |move_pips| on any liquid FX release history. On the 196-release NFP × USDJPY series (see today’s Stats for Traders #10) the lag-1 autocorrelation of |move_pips| is +0.26 — well above the ±0.14 IID confidence band. That’s a canonical GARCH signature: signed moves are essentially unforecastable (matching Fama’s 1970 weak-form efficiency (Paper Trail #4)), but the SQUARES of those moves are highly forecastable because volatility clusters into macro regimes.
Second, GARCH-style volatility forecasts are what implied- volatility surfaces are built off. Option premia in FX price in the market’s GARCH-consistent expectation of variance over the option’s life. Persistent trading edges in FX vol markets tend to be in the volatility risk premium — the wedge between implied and realised volatility — not in forecasting the level of volatility itself, because everyone is running the same GARCH-family forecast and it’s priced in.
What Bollerslev planted for later
Two seeds worth flagging. Page 309, footnote 1 (verbatim): “Instead of ε²_(t−1) in eq. (2) the absolute value of ε_(t−1) may be more appropriate in some applications; cf. McCulloch (1983).” That’s the intellectual seed of Nelson (1991) EGARCH and the entire class of asymmetric-response models (TARCH, GJR-GARCH, APARCH) where negative shocks and positive shocks have different variance impacts. In equity vol this asymmetry is called the “leverage effect”; in FX it’s the empirical basis for skew across currency pairs.
The other seed is Section 3’s Theorem 2 on finite-fourth-moment conditions for GARCH(1,1). If the fourth moment doesn’t exist, kurtosis is undefined and the whole finite-sample inference machinery breaks. Bollerslev shows the condition is met for the US inflation fit — the paper text on page 320 verifies “the condition as discussed in footnote 3 takes the value 0.989 for 0.802”, just barely under the unit-boundary. Later GARCH work (Ling & McAleer 2003 and onward) fills out the whole existence-of-moments hierarchy for higher-order GARCH models, and it all traces back to this theorem.
Author, acknowledgments, and provenance
Bollerslev was a doctoral student at UC San Diego when he wrote this paper (also affiliated with the Institute of Economics at the University of Aarhus, per the title-page affiliations). Rob Engle was on his dissertation committee at UCSD — the paper credits him in the acknowledgments alongside David Hendry. Verbatim from page 307 (footnote star): “I am grateful to David Hendry and Rob Engle for introducing me to this new idea, and to Rob Engle for many helpful discussions. I would also like to thank Sastry Pantula for suggesting the alternative parameterization, two anonymous referees for useful comments, and Kirsten Stentoft for typing the manuscript.”
Received May 1985, final version received February 1986, published in Journal of Econometrics Volume 31 (1986) pages 307-327, North-Holland. Full 21-page PDF is hosted by Bollerslev himself on his current Duke Economics faculty page at public.econ.duke.edu/~boller/Published_Papers/joe_86.pdf — every quantitative claim in this post traces to a specific passage in that PDF, extracted 2026-08-10 via pymupdf.
What this doesn’t say
The paper is quarterly-inflation, not high-frequency FX.Bollerslev’s empirical example is quarterly US GNP-deflator inflation, 143 observations over 36 years. The first application of ARCH-family models to intraday FX data is Domowitz & Hakkio (1985), which Bollerslev cites in the introduction. GARCH generalises cleanly to higher-frequency data but the specific coefficient values (α_1 = 0.135, β_1 = 0.829) are inflation-specific; the FX analog typically shows β_1 even closer to 1 because volatility persistence in liquid FX is even more pronounced than in quarterly macro data.
The GARCH(1,1) conditional-normality assumption isn’t realistic for tail buckets.Bollerslev’s assumption is ε_t | ψ_(t−1) ~ N(0, h_t). Empirical FX release data has fatter tails than conditional normality would predict (see Stats for Traders #6 on kurtosis), which is why Bollerslev & Wooldridge (1992) later introduced quasi-maximum-likelihood estimation that’s robust to conditional distributional misspecification, and why Student-t GARCH models became standard for financial applications.
GARCH doesn’t predict which way price moves; only how much it moves. This is the same efficient-markets wall Fama (1970) mapped out: forecasting the level of returns is hard-to-impossible in liquid markets, but forecasting the variability of returns is very much possible, and GARCH is the parametric tool for doing so. Any trading signal derived from a GARCH forecast is a volatility bet, not a directional one.